“泊松分布”的版本间的差异

2021年11月14日 (日) 17:24的版本

此词条暂由水流心不竞初译，未经审校，带来阅读不便，请见谅。审校：fairywang

In probability theory and statistics, the Poisson distribution (模板:IPAc-en; 模板:IPA-fr), named after French mathematician Siméon Denis Poisson, is a discrete probability distribution that expresses the probability of a given number of events occurring in a fixed interval of time or space if these events occur with a known constant mean rate and independently of the time since the last event.模板:R The Poisson distribution can also be used for the number of events in other specified intervals such as distance, area or volume.

In probability theory and statistics, the Poisson distribution (; ), named after French mathematician Siméon Denis Poisson, is a discrete probability distribution that expresses the probability of a given number of events occurring in a fixed interval of time or space if these events occur with a known constant mean rate and independently of the time since the last event. The Poisson distribution can also be used for the number of events in other specified intervals such as distance, area or volume.

在概率论和统计学中， 泊松分布 Poisson distribution是以法国数学家西莫恩·德尼·泊松 Siméon Denis Poisson命名的，是一个离散的概率分布，它表示在一个固定的时间段或空间中一定数量的事件的发生概率，这些事件以一个已知的常数平均速率发生，并且独立于与上一个事件的间隔发生时间。还可以用来表示其他有特定间隔的事件数量，如距离、面积或体积。

 --fairywang(讨论)  【审校】“它表示在一个固定的时间段或空间中一定数量的事件的发生概率”改为“它表示在一个固定的时间段或空间中，一定数量的事件发生的概率”

For instance, an individual keeping track of the amount of mail they receive each day may notice that they receive an average number of 4 letters per day. If receiving any particular piece of mail does not affect the arrival times of future pieces of mail, i.e., if pieces of mail from a wide range of sources arrive independently of one another, then a reasonable assumption is that the number of pieces of mail received in a day obeys a Poisson distribution.模板:R Other examples that may follow a Poisson distribution include the number of phone calls received by a call center per hour and the number of decay events per second from a radioactive source.

For instance, an individual keeping track of the amount of mail they receive each day may notice that they receive an average number of 4 letters per day. If receiving any particular piece of mail does not affect the arrival times of future pieces of mail, i.e., if pieces of mail from a wide range of sources arrive independently of one another, then a reasonable assumption is that the number of pieces of mail received in a day obeys a Poisson distribution. Other examples that may follow a Poisson distribution include the number of phone calls received by a call center per hour and the number of decay events per second from a radioactive source.

例如，记录每天收到邮件数量的个人可能会注意到，他们平均每天收到4封信。如果收到任何邮件都并不影响未来邮件的到达时间，也就是说，如果不同来源的邮件彼此独立地到达，那么一个合理的假设是，每天收到的邮件数量服从一个泊松分布。其他可能遵循一个泊松分布的例子包括：呼叫中心每小时接到的电话数量和每秒从放射源衰变事件的数量。

 --fairywang(讨论)  【审校】“呼叫中心每小时接到的电话数量和每秒从放射源衰变事件的数量。”改为“呼叫中心每小时接到的电话数量和每秒从放射源的衰变数。”

Definitions定义

Probability mass function概率分布函数

The Poisson distribution is popular for modeling the number of times an event occurs in an interval of time or space.

The Poisson distribution is popular for modeling the number of times an event occurs in an interval of time or space.

泊松分布模型用来模拟一个事件在一段时间或空间内发生的次数。

A discrete random variable X is said to have a Poisson distribution with parameter λ > 0, if, for k = 0, 1, 2, ..., the probability mass function of X is given by:模板:R

A discrete random variable X is said to have a Poisson distribution with parameter λ > 0, if, for k = 0, 1, 2, ..., the probability mass function of X is given by:

一个离散的随机变量 x 被称为具有参数λ > 0的泊松分布，如果对于 k = 0,1,2，... ，x 的概率分布函数是:

[math]\displaystyle{ \!f(k; \lambda)= \Pr(X = k)= \frac{\lambda^k e^{-\lambda}}{k!}, }[/math]

where

当

e is Euler's number (e = 2.71828...)

k! is the factorial of k.

The positive real number λ is equal to the expected value of X and also to its variance引用错误：没有找到与</ref>对应的<ref>标签

^[1]

^[2]

[math]\displaystyle{ \lambda=\operatorname{E}(X)=\operatorname{Var}(X). }[/math]

The Poisson distribution can be applied to systems with a large number of possible events, each of which is rare. The number of such events that occur during a fixed time interval is, under the right circumstances, a random number with a Poisson distribution.

泊松分布可以应用于包括大量罕见可能事件的系统。在正确的条件下，在一个固定的时间间隔内发生的这类事件的数量是一个具有泊松分布的随机数。

Example举例

The Poisson distribution may be useful to model events such as

泊松分布模型可以用来模拟事件，比如

The number of meteorites greater than 1 meter diameter that strike Earth in a year

The number of patients arriving in an emergency room between 10 and 11 pm

The number of laser photons hitting a detector in a particular time interval

一年内撞击地球的直径大于1米的陨石数量

晚上10点到11点到达急诊室的病人人数

在特定时间间隔内撞击探测器的激光光子数

Assumptions and validity假设与有效条件

The Poisson distribution is an appropriate model if the following assumptions are true:模板:R

The Poisson distribution is an appropriate model if the following assumptions are true:

以下假设成立时，泊松分布模型适用:

$k$ is the number of times an event occurs in an interval and $k$ can take values 0, 1, 2, ....

The occurrence of one event does not affect the probability that a second event will occur. That is, events occur independently.

The average rate at which events occur is independent of any occurrences. For simplicity, this is usually assumed to be constant, but may in practice vary with time.

Two events cannot occur at exactly the same instant; instead, at each very small sub-interval exactly one event either occurs or does not occur.

事件在一个时间间隔内发生且{mvar | k}可以取值0，1，2，...；

一个事件的发生不影响第二个事件发生的概率，也就是时间发生相互独立；

事件发生的平均速率与任何事件无关。为简单起见，通常假定其为常数，但实际上可能随时间而变化；

两个事件不可能在完全相同的时刻发生，即在每一小段的时间内正好有一个事件发生或不发生。

If these conditions are true, then $k$ is a Poisson random variable, and the distribution of $k$ is a Poisson distribution.

If these conditions are true, then is a Poisson random variable, and the distribution of is a Poisson distribution.

如果这些条件成立，那么它是一个泊松随机变量，其分布是一个 {泊松分布 Poisson distribution。

The Poisson distribution is also the limit of a binomial distribution, for which the probability of success for each trial equals $λ$ divided by the number of trials, as the number of trials approaches infinity (see Related distributions).

The Poisson distribution is also the limit of a binomial distribution, for which the probability of success for each trial equals divided by the number of trials, as the number of trials approaches infinity (see Related distributions). 每次试验的成功概率除以总试验次数，随着试验的数量趋于无穷大，泊松分布也是 二项式分布Binomial distribution的极限。（可参考相关分布）

Probability of events for a Poisson distribution {泊松分布 Poisson distribution的事件概率

An event can occur 0, 1, 2, ... times in an interval. The average number of events in an interval is designated [math]\displaystyle{ \lambda }[/math] (lambda). [math]\displaystyle{ \lambda }[/math] is the event rate, also called the rate parameter. The probability of observing $k$ events in an interval is given by the equation

An event can occur 0, 1, 2, ... times in an interval. The average number of events in an interval is designated [math]\displaystyle{ \lambda }[/math] (lambda). [math]\displaystyle{ \lambda }[/math] is the event rate, also called the rate parameter. The probability of observing events in an interval is given by the equation

一个事件可以在一个间隔内发生0,1,2，... 次。区间内的平均事件数被指定为 < math > lambda </math > (lambda)。Lambda </math > 是事件速率Event rate ，也称为 速率参数Rate parameter。以下方程给出了在一个区间内观测事件的概率

[math]\displaystyle{ P(k \text{ events in interval}) = \frac{\lambda^k e^{-\lambda}}{k!} }[/math]

< math > p (k text { events in interval }) = frac { lambda ^ k e ^ {-lambda }{ k！{/math >

where

当

[math]\displaystyle{ \lambda }[/math] is the average number of events per interval

e is the number 2.71828... (Euler's number) the base of the natural logarithms

$k$ takes values 0, 1, 2, ...

$k$ ! = $k$ × ( $k$ − 1) × ( $k$ − 2) × ... × 2 × 1 is the factorial of $k$ .

This equation is the probability mass function (PMF) for a Poisson distribution.

这个方程就是概率质量函数的泊松分布。

This equation can be adapted if, instead of the average number of events [math]\displaystyle{ \lambda }[/math], we are given a time rate [math]\displaystyle{ r }[/math] for the events to happen. Then [math]\displaystyle{ \lambda = r t }[/math] (with [math]\displaystyle{ r }[/math] in units of 1/time), and

如果不用事件的平均数字 < math > lambda </math > ，而是给出事件发生的时间率 < math > r </math > ，那么这个方程就可以适用。然后是 < math > > lambda = r t </math > (以1/time 为单位的 < math > r </math >) ，以及

 --fairywang(讨论)  【审校】“那么这个方程就可以适用”改为“那么这个方程就是适用的”

[math]\displaystyle{ P(k \text{ events in interval } t) = \frac{(r t)^k e^{-r t}}{k!} }[/math]

< math > p (k text { events in interval } t) = frac {(r t) ^ k e ^ {-r t }{ k！{/math >

Examples of probability for Poisson distributions {泊松分布 Poisson distribution概率的示例

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On a particular river, overflow floods occur once every 100 years on average. Calculate the probability of $k$ = 0, 1, 2, 3, 4, 5, or 6 overflow floods in a 100-year interval, assuming the Poisson model is appropriate.

On a particular river, overflow floods occur once every 100 years on average. Calculate the probability of = 0, 1, 2, 3, 4, 5, or 6 overflow floods in a 100-year interval, assuming the Poisson model is appropriate.

在某一条河流上，洪水平均每100年发生泛滥一次。计算在100年间洪水泛滥次数= 0,1,2,3,4,5，或6次的概率，假设（其分布）适用泊松模型。

 --fairywang(讨论)  【审校】“计算在100年间洪水泛滥次数= 0,1,2,3,4,5或6次的概率”

Because the average event rate is one overflow flood per 100 years, λ = 1

因为平均事件率是每100年发一次洪水，λ = 1

[math]\displaystyle{ P(k \text{ overflow floods in 100 years}) = \frac{\lambda^k e^{-\lambda}}{k!} = \frac{1^k e^{-1}}{k!} }[/math]

[math]\displaystyle{  P(k \text{ overflow floods in 100 years}) = \frac{\lambda^k e^{-\lambda}}{k!} = \frac{1^k e^{-1}}{k!} }[/math]

< math > p (k text { overflow in 100 years }) = frac { lambda ^ k e ^ {-lambda }}{ k! }= frac {1 ^ k e ^ {-1}{ k！{/math >

[math]\displaystyle{ P(k = 0 \text{ overflow floods in 100 years}) = \frac{1^0 e^{-1}}{0!} = \frac{e^{-1}}{1} \approx 0.368 }[/math]

[math]\displaystyle{  P(k = 0 \text{ overflow floods in 100 years}) = \frac{1^0 e^{-1}}{0!} = \frac{e^{-1}}{1} \approx 0.368  }[/math]

< math > p (k = 0 text { overflow flood in 100 years }) = frac {1 ^ 0 e ^ {-1}{0! }= frac { e ^ {-1}{1}约0.368 </math >

[math]\displaystyle{ P(k = 1 \text{ overflow flood in 100 years}) = \frac{1^1 e^{-1}}{1!} = \frac{e^{-1}}{1} \approx 0.368 }[/math]

[math]\displaystyle{  P(k = 1 \text{ overflow flood in 100 years}) = \frac{1^1 e^{-1}}{1!} = \frac{e^{-1}}{1} \approx 0.368  }[/math]

< math > p (k = 1 text { overflow flood in 100 years }) = frac {1 ^ 1 e ^ {-1}{1! }= frac { e ^ {-1}{1}约0.368 </math >

[math]\displaystyle{ P(k = 2 \text{ overflow floods in 100 years}) = \frac{1^2 e^{-1}}{2!} = \frac{e^{-1}}{2} \approx 0.184 }[/math]

[math]\displaystyle{  P(k = 2 \text{ overflow floods in 100 years}) = \frac{1^2 e^{-1}}{2!} = \frac{e^{-1}}{2} \approx 0.184  }[/math]

< math > p (k = 2 text { overflow flood in 100 years }) = frac {1 ^ 2 e ^ {-1}{2! }= frac { e ^ {-1}{2} approx 0.184 </math >

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The table below gives the probability for 0 to 6 overflow floods in a 100-year period.

下表给出了100年内0到6次洪水泛滥的概率。

{ | class = “ wikitable”

$k$	P( $k$ overflow floods in 100 years)		P( overflow floods in 100 years)		100年内泛滥成灾
0	0.368	0	0.368	0	0.368
1	0.368	1	0.368	1	0.368
2	0.184	2	0.184	2	0.184
3	0.061	3	0.061	3	0.061
4	0.015	4	0.015	4	0.015
5	0.003	5	0.003	5	0.003
6	0.0005	6	0.0005	6	0.0005

|}

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Ugarte and colleagues report that the average number of goals in a World Cup soccer match is approximately 2.5 and the Poisson model is appropriate.模板:R

Ugarte and colleagues report that the average number of goals in a World Cup soccer match is approximately 2.5 and the Poisson model is appropriate.

乌加特和他的同事们在一篇报道中提到，世界杯足球赛的平均进球数约为2.5个，这也适用泊松模型。

Because the average event rate is 2.5 goals per match, λ = 2.5.

因为平均每场比赛有2.5个进球，λ = 2.5个。

[math]\displaystyle{ P(k \text{ goals in a match}) = \frac{2.5^k e^{-2.5}}{k!} }[/math]

[math]\displaystyle{  P(k \text{ goals in a match}) = \frac{2.5^k e^{-2.5}}{k!} }[/math]

< math > p (k text { goals in a match }) = frac {2.5 ^ k e ^ {-2.5}{ k！{/math >

[math]\displaystyle{ P(k = 0 \text{ goals in a match}) = \frac{2.5^0 e^{-2.5}}{0!} = \frac{e^{-2.5}}{1} \approx 0.082 }[/math]

[math]\displaystyle{  P(k = 0 \text{ goals in a match}) = \frac{2.5^0 e^{-2.5}}{0!} = \frac{e^{-2.5}}{1} \approx 0.082  }[/math]

= frac {2.5 ^ 0 e ^ {-2.5}{0! }= frac { e ^ {-2.5}{1}大约0.082

[math]\displaystyle{ P(k = 1 \text{ goal in a match}) = \frac{2.5^1 e^{-2.5}}{1!} = \frac{2.5 e^{-2.5}}{1} \approx 0.205 }[/math]

[math]\displaystyle{  P(k = 1 \text{ goal in a match}) = \frac{2.5^1 e^{-2.5}}{1!} = \frac{2.5 e^{-2.5}}{1} \approx 0.205  }[/math]

= frac {2.5 ^ 1 e ^ {-2.5}{1! }= frac {2.5 e ^ {-2.5}{1}约0.205

[math]\displaystyle{ P(k = 2 \text{ goals in a match}) = \frac{2.5^2 e^{-2.5}}{2!} = \frac{6.25 e^{-2.5}}{2} \approx 0.257 }[/math]

[math]\displaystyle{  P(k = 2 \text{ goals in a match}) = \frac{2.5^2 e^{-2.5}}{2!} = \frac{6.25 e^{-2.5}}{2} \approx 0.257  }[/math]

< math > p (k = 2 text { goals in a match }) = frac {2.5 ^ 2 e ^ {-2.5}{2! }= frac {6.25 e ^ {-2.5}{2}{2}{约0.257 </math >

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The table below gives the probability for 0 to 7 goals in a match.

下表给出了一场比赛中0到7个进球的概率。

{ | class = “ wikitable”

$k$	P( $k$ goals in a World Cup soccer match)		P( goals in a World Cup soccer match)		P (世界杯足球赛进球)
0	0.082	0	0.082	0	0.082
1	0.205	1	0.205	1	0.205
2	0.257	2	0.257	2	0.257
3	0.213	3	0.213	3	0.213
4	0.133	4	0.133	4	0.133
5	0.067	5	0.067	5	0.067
6	0.028	6	0.028	6	0.028
7	0.010	7	0.010	7	0.010

|}

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Once in an interval events: The special case of λ = 1 and k = 0 事件唯一发生：λ = 1 与 k = 0的特殊情形

Suppose that astronomers estimate that large meteorites (above a certain size) hit the earth on average once every 100 years (λ = 1 event per 100 years), and that the number of meteorite hits follows a Poisson distribution. What is the probability of $k$ = 0 meteorite hits in the next 100 years?

Suppose that astronomers estimate that large meteorites (above a certain size) hit the earth on average once every 100 years (λ = 1 event per 100 years), and that the number of meteorite hits follows a Poisson distribution. What is the probability of = 0 meteorite hits in the next 100 years?

假设天文学家估计，大型陨石(超过一定大小)平均每100年撞击地球一次(= 每100年撞击一次) ，而且陨石撞击的次数服从泊松分布。在接下来的100年里，被陨石击中k=0的概率是多少？

 --fairywang(讨论)  【审校】“而且陨石撞击的次数紧随泊松分布之后”改为“而且陨石撞击的次数紧随泊松分布之后”

[math]\displaystyle{ P(k = \text{0 meteorites hit in next 100 years}) = \frac{1^0 e^{-1}}{0!} = \frac{1}{e} \approx 0.37 }[/math]

[math]\displaystyle{  P(k = \text{0 meteorites hit in next 100 years}) = \frac{1^0 e^{-1}}{0!} = \frac{1}{e} \approx 0.37  }[/math]

< math > p (k = text {0 meteorites hit in next 100 years }) = frac {1 ^ 0 e ^ {-1}{0! }= frac {1}{ e }大约0.37 </math >

Under these assumptions, the probability that no large meteorites hit the earth in the next 100 years is roughly 0.37. The remaining 1 − 0.37 = 0.63 is the probability of 1, 2, 3, or more large meteorite hits in the next 100 years.

根据这些假设，未来100年内没有大陨石撞击地球的概率大约为0.37。剩下的1-0.37 = 0.63是未来100年内被1,2,3或更多大型陨石撞击的概率。

In an example above, an overflow flood occurred once every 100 years (λ = 1). The probability of no overflow floods in 100 years was roughly 0.37, by the same calculation.

在上面的一个例子中，洪水每100年发生泛滥一次(λ= 1)。根据同样的计算，100年内不会有洪水泛滥的概率大约是0.37。

In general, if an event occurs on average once per interval (λ = 1), and the events follow a Poisson distribution, then P(0 events in next interval) = 0.37. In addition, P(exactly one event in next interval) = 0.37, as shown in the table for overflow floods.

In general, if an event occurs on average once per interval (λ = 1), and the events follow a Poisson distribution, then . In addition, P(exactly one event in next interval) = 0.37, as shown in the table for overflow floods.

一般来说，如果一个事件平均每个时间间隔发生一次(λ= 1) ，并且事件遵循泊松分布，那么p (下一个间隔中正好有一个事件) = 0.37，如洪水泛滥的表所示。

Examples that violate the Poisson assumptions 违反泊松假设的例子

The number of students who arrive at the student union per minute will likely not follow a Poisson distribution, because the rate is not constant (low rate during class time, high rate between class times) and the arrivals of individual students are not independent (students tend to come in groups).

每分钟抵达学生会的学生人数可能不会遵循一个 泊松分布Poisson distribution.，因为这个比率不是恒定的(上课时间的低比率，课间时的高比率) ，而且每个学生的到达也不是独立的(学生往往是成群结队来的)。

The number of magnitude 5 earthquakes per year in a country may not follow a Poisson distribution if one large earthquake increases the probability of aftershocks of similar magnitude.

一次大的强震会增加发生类似震级余震的可能性，那么一个国家每年发生5级地震的次数可能不会服从 泊松分布Poisson distribution.。

 --fairywang(讨论)  【审校】“泊松分布”改为“泊松分布”

Examples in which at least one event is guaranteed are not Poission distributed; but may be modeled using a Zero-truncated Poisson distribution.

至少有一个事件确定发生的情况不是 Poission 分布式的，但也许可以使用零截断 泊松分布Poisson distribution.进行建模。

 --fairywang(讨论)  【审校】“泊松分布”改为“泊松分布”

Count distributions in which the number of intervals with zero events is higher than predicted by a Poisson model may be modeled using a Zero-inflated model.

如果零事件的区间数高于泊松模型预测的区间数分布，则可以使用零膨胀模型来建模。

Properties 性能

描述统计学Descriptive statistics

The expected value and variance of a Poisson-distributed random variable are both equal to λ.

一个泊松分布随机变量的期望值和方差均等于λ

The coefficient of variation is [math]\displaystyle{ \textstyle \lambda^{-1/2} }[/math], while the index of dispersion is 1.模板:R

当index of dispersion is 1.模板:R，相关系数为[math]\displaystyle{ \textstyle \lambda^{-1/2} }[/math]

The mean absolute deviation about the mean is模板:R

均值的绝对平均差为模板:R

[math]\displaystyle{ \operatorname{E}[|X-\lambda|]= \frac{2 \lambda^{\lfloor\lambda\rfloor + 1} e^{-\lambda}}{\lfloor\lambda\rfloor!}. }[/math]

[ | x-lambda | ] = frac {2 lambda ^ { lfloor lambda rfloor + 1} e ^ {-lambda }{ lfloor lambda rfloor！} . </math >

The mode of a Poisson-distributed random variable with non-integer λ is equal to [math]\displaystyle{ \scriptstyle\lfloor \lambda \rfloor }[/math], which is the largest integer less than or equal to λ. This is also written as floor(λ). When λ is a positive integer, the modes are λ and λ − 1.

All of the cumulants of the Poisson distribution are equal to the expected value λ. The nth factorial moment of the Poisson distribution is λⁿ.

The expected value of a Poisson process is sometimes decomposed into the product of intensity and exposure (or more generally expressed as the integral of an "intensity function" over time or space, sometimes described as “exposure”).模板:R

一个具有非整值λ 的泊松分布随机变量的统计值等于[math]\displaystyle{ \scriptstyle\lfloor \lambda \rfloor }[/math], 小于λ的最大整数。它也写作floor(λ). λ为正整数时，取值为λ 以及 λ − 1。
所有泊松分布的积均等于期望值 λ。泊松分布的n阶指数积为λⁿ。
期望值与泊松过程有时分解为“强度”与“面积”的乘积（或更一般地表示为强度函数随时间或空间的积分，有时描述为暴露 exposure。）

Median 中值

Bounds for the median ([math]\displaystyle{ \nu }[/math]) of the distribution are known and are sharp:模板:R

Bounds for the median ([math]\displaystyle{ \nu }[/math]) of the distribution are known and are sharp:

分布的中位数(< math > nu </math >)的界限为已知，且清晰:

[math]\displaystyle{ \lambda - \ln 2 \le \nu \lt \lambda + \frac{1}{3}. }[/math]

[math]\displaystyle{  \lambda - \ln 2 \le \nu \lt  \lambda + \frac{1}{3}.  }[/math]

2 le nu < lambda + frac {1}{3}.数学

Higher moments 高阶矩

The higher moments m_k of the Poisson distribution about the origin are touchard polynomials in λ:

[math]\displaystyle{ m_k = \sum_{i=0}^k \lambda^i \left\{\begin{matrix} k \\ i \end{matrix}\right\}, }[/math]

[math]\displaystyle{  m_k = \sum_{i=0}^k \lambda^i \left\{\begin{matrix} k \\ i \end{matrix}\right\}, }[/math]

< math > m _ k = sum { i = 0} ^ k lambda ^ i left { begin { matrix } k i end { matrix } right } ，</math >

泊松分布原点的高阶矩moments m_k是同余多项式，λ中：

where the {braces} denote Stirling numbers of the second kind.模板:R 模板:R The coefficients of the polynomials have a combinatorial meaning. In fact, when the expected value of the Poisson distribution is 1, then Dobinski's formula says that the nth moment equals the number of partitions of a set of size n.

where the {braces} denote Stirling numbers of the second kind. The coefficients of the polynomials have a combinatorial meaning. In fact, when the expected value of the Poisson distribution is 1, then Dobinski's formula says that the nth moment equals the number of partitions of a set of size n.

其中{括号}表示第二类 Stirling 数。多项式的系数具有组合意义。事实上，当泊松分布的期望值是1时，那么 Dobinski 的公式说第 n 个时刻等于一组大小为 n 的分区的数目。

 --fairywang(讨论)  【审校】“泊松分布”改为“泊松分布”

For the non-centered moments we define [math]\displaystyle{ B=k/\lambda }[/math], then模板:R

For the non-centered moments we define [math]\displaystyle{ B=k/\lambda }[/math], then

对于非中心时刻，我们定义了 < math > b = k/lambda </math >

[math]\displaystyle{ \lt math\gt 《数学》 E[X^k]^{1/k} \le C\cdot E[X^k]^{1/k} \le C\cdot E [ x ^ k ] ^ {1/k } le c dot \begin{cases} \begin{cases} 开始{ cases } k/B & \text{if}\quad B \lt e \\ k/B & \text{if}\quad B \lt e \\ k/B & text { if }方 b \lt e k/\log B & \text{if}\quad B\ge e k/\log B & \text{if}\quad B\ge e 如果你想要一个更好的工具，你需要一个更好的工具 \end{cases} \end{cases} 结束{ cases } }[/math]

</math>

数学

where [math]\displaystyle{ C }[/math] is some absolute constant greater than 0.

其中，c </math > 是某个大于0的绝对常数。

Sums of Poisson-distributed random variables 泊松分布随机变量和

If [math]\displaystyle{ X_i \sim \operatorname{Pois}(\lambda_i) }[/math] for [math]\displaystyle{ i=1,\dotsc,n }[/math] are independent, then [math]\displaystyle{ \sum_{i=1}^n X_i \sim \operatorname{Pois}\left(\sum_{i=1}^n \lambda_i\right) }[/math].模板:R A converse is Raikov's theorem, which says that if the sum of two independent random variables is Poisson-distributed, then so are each of those two independent random variables.模板:R 模板:R

If [math]\displaystyle{ X_i \sim \operatorname{Pois}(\lambda_i) }[/math] for [math]\displaystyle{ i=1,\dotsc,n }[/math] are independent, then [math]\displaystyle{ \sum_{i=1}^n X_i \sim \operatorname{Pois}\left(\sum_{i=1}^n \lambda_i\right) }[/math]. A converse is Raikov's theorem, which says that if the sum of two independent random variables is Poisson-distributed, then so are each of those two independent random variables.

如果对于 < math > i = 1，dotsc，n </math > 是独立的，那么 < math > sum { i = 1} ^ n xi sim 操作者名{ Pois }左(sum { i = 1} ^ n lambda _ i 右) </math > 。一个逆定理是雷科夫定理，它说如果两个独立的随机变量之和是 泊松分布Poisson distribution.的，那么这两个独立的随机变量之和也是 泊松分布Poisson distribution.的。

 --fairywang(讨论)  【审校】“泊松分布”改为“泊松分布”

Other properties 其他特性

The Poisson distributions are infinitely divisible probability distributions.模板:R 模板:R

The directed Kullback–Leibler divergence of [math]\displaystyle{ \operatorname{Pois}(\lambda_0) }[/math] from [math]\displaystyle{ \operatorname{Pois}(\lambda) }[/math] is given by

泊松分布是无限可除概率分布，模板:R 模板:R。
[math]\displaystyle{ \operatorname{Pois}(\lambda_0) }[/math] from [math]\displaystyle{ \operatorname{Pois}(\lambda) }[/math] 的直接 相对熵（K-L散度）Kullback–Leibler divergence由以下给出：

[math]\displaystyle{ \operatorname{D}_{\text{KL}}(\lambda\mid\lambda_0) = \lambda_0 - \lambda + \lambda \log \frac{\lambda}{\lambda_0}. }[/math]

[math]\displaystyle{ \operatorname{D}_{\text{KL}}(\lambda\mid\lambda_0) = \lambda_0 - \lambda + \lambda \log \frac{\lambda}{\lambda_0}. }[/math]

< math > operatorname { d }{ text { KL }}(lambda mid lambda _ 0) = lambda _ 0-lambda + lambda log frac { lambda }{ lambda _ 0} . </math >

Bounds for the tail probabilities of a Poisson random variable [math]\displaystyle{ X \sim \operatorname{Pois}(\lambda) }[/math] can be derived using a Chernoff bound argument.模板:R
泊松随机变量尾概率的界[math]\displaystyle{ X \sim \operatorname{Pois}(\lambda) }[/math] 可以用''' 切诺夫界Chernoff bound'''参数派生模板:R

[math]\displaystyle{ P(X \geq x) \leq \frac{(e \lambda)^x e^{-\lambda}}{x^x}, \text{ for } x \gt \lambda }[/math],

[math]\displaystyle{  P(X \geq x) \leq \frac{(e \lambda)^x e^{-\lambda}}{x^x}, \text{ for } x \gt  \lambda }[/math],

(x x x) leq frac {(e lambda) ^ x e ^ {-lambda }{ x ^ x } ，text { for } x > lambda </math > ,

[math]\displaystyle{ P(X \leq x) \leq \frac{(e \lambda)^x e^{-\lambda} }{x^x}, \text{ for } x \lt \lambda. }[/math]

[math]\displaystyle{  P(X \leq x) \leq \frac{(e \lambda)^x e^{-\lambda} }{x^x}, \text{ for } x \lt  \lambda. }[/math]

< math > p (x leq x) leq frac {(e lambda) ^ x e ^ {-lambda }{ x ^ x } ，text { for } x < lambda. </math >

The upper tail probability can be tightened (by a factor of at least two) as follows:模板:R

长尾概率可被收紧（至少两倍）如下：模板:R

[math]\displaystyle{ P(X \geq x) \leq \frac{e^{-\operatorname{D}_{\text{KL}}(x\mid\lambda)}}{\max{(2, \sqrt{4\pi\operatorname{D}_{\text{KL}}(x\mid\lambda)}})}, \text{ for } x \gt \lambda, }[/math]

[math]\displaystyle{  P(X \geq x) \leq \frac{e^{-\operatorname{D}_{\text{KL}}(x\mid\lambda)}}{\max{(2, \sqrt{4\pi\operatorname{D}_{\text{KL}}(x\mid\lambda)}})}, \text{ for } x \gt  \lambda, }[/math]

< math > p (x geq x) leq frac { e ^ {-operatorname { d }{ text { KL }(x mid lambda)}}{ max {(2，sqrt {4 pi operatorname { d }{ text { KL }(x mid lambda)}}}}) ，text { for } x > lambda，</math >

where [math]\displaystyle{ \operatorname{D}_{\text{KL}}(x\mid\lambda) }[/math] is the directed Kullback–Leibler divergence, as described above.

where [math]\displaystyle{ \operatorname{D}_{\text{KL}}(x\mid\lambda) }[/math] is the directed Kullback–Leibler divergence, as described above.

其中 < math > operatorname { d } _ { text { KL }}(x mid lambda) </math > 是指向的 Kullback-Leibler 分歧，如上所述。

Inequalities that relate the distribution function of a Poisson random variable [math]\displaystyle{ X \sim \operatorname{Pois}(\lambda) }[/math] to the Standard normal distribution function [math]\displaystyle{ \Phi(x) }[/math] are as follows:模板:R

关于泊松随机变量分布函数的不等式 [math]\displaystyle{ X \sim \operatorname{Pois}(\lambda) }[/math]与标准正态分布函数[math]\displaystyle{ \Phi(x) }[/math] 如下:模板:R

[math]\displaystyle{ \Phi\left(\operatorname{sign}(k-\lambda)\sqrt{2\operatorname{D}_{\text{KL}}(k\mid\lambda)}\right) \lt P(X \leq k) \lt \Phi\left(\operatorname{sign}(k-\lambda+1)\sqrt{2\operatorname{D}_{\text{KL}}(k+1\mid\lambda)}\right), \text{ for } k \gt 0, }[/math]

[math]\displaystyle{  \Phi\left(\operatorname{sign}(k-\lambda)\sqrt{2\operatorname{D}_{\text{KL}}(k\mid\lambda)}\right) \lt  P(X \leq k) \lt  \Phi\left(\operatorname{sign}(k-\lambda+1)\sqrt{2\operatorname{D}_{\text{KL}}(k+1\mid\lambda)}\right), \text{ for } k \gt  0, }[/math]

< math > Phi left (operatorname { sign }(k-lambda) sqrt {2 operatorname { d }{ text { KL }(k mid lambda)}右) 0，</math >

where [math]\displaystyle{ \operatorname{D}_{\text{KL}}(k\mid\lambda) }[/math] is again the directed Kullback–Leibler divergence.

where [math]\displaystyle{ \operatorname{D}_{\text{KL}}(k\mid\lambda) }[/math] is again the directed Kullback–Leibler divergence.

其中 < math > 操作者名{ d } _ { text { KL }(k mid lambda) </math > 仍然是有向的 Kullback-Leibler 分歧。

Poisson races 泊松族群

Let [math]\displaystyle{ X \sim \operatorname{Pois}(\lambda) }[/math] and [math]\displaystyle{ Y \sim \operatorname{Pois}(\mu) }[/math] be independent random variables, with [math]\displaystyle{ \lambda \lt \mu }[/math], then we have that

设 x sim 操作者名称{ Pois }(lambda) </math > 和 < math > y sim 操作者名称{ Pois }(mu) </math > 是独立的随机变量，并且带有 < math > lambda < mu </math > ，那么我们就有了

[math]\displaystyle{ \lt math\gt 《数学》 \frac{e^{-(\sqrt{\mu} -\sqrt{\lambda})^2 }}{(\lambda + \mu)^2} - \frac{e^{-(\lambda + \mu)}}{2\sqrt{\lambda \mu}} - \frac{e^{-(\lambda + \mu)}}{4\lambda \mu} \leq P(X - Y \geq 0) \leq e^{- (\sqrt{\mu} -\sqrt{\lambda})^2} \frac{e^{-(\sqrt{\mu} -\sqrt{\lambda})^2 }}{(\lambda + \mu)^2} - \frac{e^{-(\lambda + \mu)}}{2\sqrt{\lambda \mu}} - \frac{e^{-(\lambda + \mu)}}{4\lambda \mu} \leq P(X - Y \geq 0) \leq e^{- (\sqrt{\mu} -\sqrt{\lambda})^2} Frac { e ^ {-(sqrt { mu }-sqrt { lambda }) ^ 2}{(lambda + mu) ^ 2}-frac { e ^ {-(lambda + mu)}}{2 sqrt { lambda mu }-frac { e ^ { e ^ {-(lambda + mu)}-(lambda + mu)}}}{4 lambda } leq p (x-y geq 0) leq ^ e ^ {-(sqrt { mu }-sqrt { lambda }) ^ 2} }[/math]

</math>

数学

The upper bound is proved using a standard Chernoff bound.

利用标准的 切诺夫界Chernoff bound证明了上界的存在性。

The lower bound can be proved by noting that [math]\displaystyle{ P(X-Y\geq0\mid X+Y=i) }[/math] is the probability that [math]\displaystyle{ Z \geq \frac{i}{2} }[/math], where [math]\displaystyle{ Z \sim \operatorname{Bin}\left(i, \frac{\lambda}{\lambda+\mu}\right) }[/math], which is bounded below by [math]\displaystyle{ \frac{1}{(i+1)^2} e^{\left(-iD\left(0.5 \| \frac{\lambda}{\lambda+\mu}\right)\right)} }[/math], where [math]\displaystyle{ D }[/math] is relative entropy (See the entry on bounds on tails of binomial distributions for details). Further noting that [math]\displaystyle{ X+Y \sim \operatorname{Pois}(\lambda+\mu) }[/math], and computing a lower bound on the unconditional probability gives the result. More details can be found in the appendix of Kamath et al..模板:R

The lower bound can be proved by noting that [math]\displaystyle{ P(X-Y\geq0\mid X+Y=i) }[/math] is the probability that [math]\displaystyle{ Z \geq \frac{i}{2} }[/math], where [math]\displaystyle{ Z \sim \operatorname{Bin}\left(i, \frac{\lambda}{\lambda+\mu}\right) }[/math], which is bounded below by [math]\displaystyle{ \frac{1}{(i+1)^2} e^{\left(-iD\left(0.5 \| \frac{\lambda}{\lambda+\mu}\right)\right)} }[/math], where [math]\displaystyle{ D }[/math] is relative entropy (See the entry on bounds on tails of binomial distributions for details). Further noting that [math]\displaystyle{ X+Y \sim \operatorname{Pois}(\lambda+\mu) }[/math], and computing a lower bound on the unconditional probability gives the result. More details can be found in the appendix of Kamath et al..

下限可以通过下面的例子来证明: < math > p (X-Y geq0 mid x + y = i) </math > 是 < math > z geq frac { i }{2} </math > ，其中 < math > z sim 操作员名{ Bin }左(i，frac { lambda } + mu }右) </math > ,下面由 < math > frac {1}{(i + 1) ^ 2} e ^ { left (- iD left (0.5 | frac { lambda }(- iD left (0.5 | frac { lambda + mu } right)}}} </math > 限定，其中 < math > d </math > 是相对熵。进一步注意到 < math > x + y sim 操作者名{ Pois }(lambda + mu) </math > ，并计算无条件概率的下限得到结果。更多的细节可以在卡马斯等人的附录中找到。

' 相关分布'Related distributions

Genera通常l

 --fairywang(讨论)  【审校】“Genera通常l”改为“General通常”

If [math]\displaystyle{ X_1 \sim \mathrm{Pois}(\lambda_1)\, }[/math] and [math]\displaystyle{ X_2 \sim \mathrm{Pois}(\lambda_2)\, }[/math] are independent, then the difference [math]\displaystyle{ Y = X_1 - X_2 }[/math] follows a Skellam distribution.

If [math]\displaystyle{ X_1 \sim \mathrm{Pois}(\lambda_1)\, }[/math] and [math]\displaystyle{ X_2 \sim \mathrm{Pois}(\lambda_2)\, }[/math] are independent, then the distribution of [math]\displaystyle{ X_1 }[/math] conditional on [math]\displaystyle{ X_1+X_2 }[/math] is a binomial distribution.

Specifically, if [math]\displaystyle{ X_1+X_2=k }[/math], then [math]\displaystyle{ \!X_1\sim \mathrm{Binom}(k, \lambda_1/(\lambda_1+\lambda_2)) }[/math].

具体来说，如果 < math > x _ 1 + x _ 2 = k </math > ，那么 < math > ! x _ 1 sim mathrm { Binom }(k，lambda _ 1/(lambda _ 1 + lambda _ 2)) </math > 。

More generally, if X₁, X₂,..., X_n are independent Poisson random variables with parameters λ₁, λ₂,..., λ_n then

更一般地说，如果 x 1 ，x 2 ，... ，x n 是独立的随机变量，参数 1 ， 2 ，... ， n 然后

given [math]\displaystyle{ \sum_{j=1}^n X_j=k, }[/math] [math]\displaystyle{ X_i \sim \mathrm{Binom}\left(k, \frac{\lambda_i}{\sum_{j=1}^n\lambda_j}\right) }[/math]. In fact, [math]\displaystyle{ \{X_i\} \sim \mathrm{Multinom}\left(k, \left\{\frac{\lambda_i}{\sum_{j=1}^n\lambda_j}\right\}\right) }[/math].

given [math]\displaystyle{ \sum_{j=1}^n X_j=k, }[/math] [math]\displaystyle{ X_i \sim \mathrm{Binom}\left(k, \frac{\lambda_i}{\sum_{j=1}^n\lambda_j}\right) }[/math]. In fact, [math]\displaystyle{ \{X_i\} \sim \mathrm{Multinom}\left(k, \left\{\frac{\lambda_i}{\sum_{j=1}^n\lambda_j}\right\}\right) }[/math].

给定的数学公式 sum { j = 1} ^ n x _ j = k，</math > x _ i sim mathrm { Binom }左(k，frac { lambda _ i }{ sum { j = 1} ^ n lambda _ j }右) </math > 。事实上，[ math ]{ xi } sim mathrm { mothom } left (k，left { frac { lambda _ i }{ sum { j = 1} ^ n lambda _ j } right }}) </math > 。

If [math]\displaystyle{ X \sim \mathrm{Pois}(\lambda)\, }[/math] and the distribution of [math]\displaystyle{ Y }[/math], conditional on X = k, is a binomial distribution, [math]\displaystyle{ Y \mid (X = k) \sim \mathrm{Binom}(k, p) }[/math], then the distribution of Y follows a Poisson distribution [math]\displaystyle{ Y \sim \mathrm{Pois}(\lambda \cdot p)\, }[/math]. In fact, if [math]\displaystyle{ \{Y_i\} }[/math], conditional on X = k, follows a multinomial distribution, [math]\displaystyle{ \{Y_i\} \mid (X = k) \sim \mathrm{Multinom}\left(k, p_i\right) }[/math], then each [math]\displaystyle{ Y_i }[/math] follows an independent Poisson distribution [math]\displaystyle{ Y_i \sim \mathrm{Pois}(\lambda \cdot p_i), \rho(Y_i, Y_j) = 0 }[/math].

The Poisson distribution can be derived as a limiting case to the binomial distribution as the number of trials goes to infinity and the expected number of successes remains fixed — see law of rare events below. Therefore, it can be used as an approximation of the binomial distribution if n is sufficiently large and p is sufficiently small. There is a rule of thumb stating that the Poisson distribution is a good approximation of the binomial distribution if n is at least 20 and p is smaller than or equal to 0.05, and an excellent approximation if n ≥ 100 and np ≤ 10.模板:R

[math]\displaystyle{ F_\mathrm{Binomial}(k;n, p) \approx F_\mathrm{Poisson}(k;\lambda=np)\, }[/math]

[math]\displaystyle{ F_\mathrm{Binomial}(k;n, p) \approx F_\mathrm{Poisson}(k;\lambda=np)\, }[/math]

(k; n，p)接近 f _ mathrm { Poisson }(k; lambda = np) ，</math >

The Poisson distribution is a special case of the discrete compound Poisson distribution (or stuttering Poisson distribution) with only a parameter.模板:R The discrete compound Poisson distribution can be deduced from the limiting distribution of univariate multinomial distribution. It is also a special case of a compound Poisson distribution.
这一泊松分布是离散复合泊松分布（或断续泊松分布）在只有一个参数情况下的特殊情形。模板:R离散复合泊松分布可由一元多项式分布的极限分布导出。同时它也是复合泊松分布#特殊情况复合泊松分布的一个特例。

For sufficiently large values of λ, (say λ>1000), the normal distribution with mean λ and variance λ (standard deviation [math]\displaystyle{ \sqrt{\lambda} }[/math]) is an excellent approximation to the Poisson distribution. If λ is greater than about 10, then the normal distribution is a good approximation if an appropriate continuity correction is performed, i.e., if P(X ≤ x), where x is a non-negative integer, is replaced by P(X ≤ x + 0.5).
对于足够大的值λ，（如 λ>1000)，具有均值 λ 的正态分布与变量 λ （标准差 [math]\displaystyle{ \sqrt{\lambda} }[/math]），是泊松分布的完美近似。如果 λ 大于10，则正态分布在适当的校正下可近似模拟，例如如果P(X ≤ x)，x 为非负整数，则将其改为P(X ≤ x + 0.5)。

[math]\displaystyle{ F_\mathrm{Poisson}(x;\lambda) \approx F_\mathrm{normal}(x;\mu=\lambda,\sigma^2=\lambda)\, }[/math]

[math]\displaystyle{ F_\mathrm{Poisson}(x;\lambda) \approx F_\mathrm{normal}(x;\mu=\lambda,\sigma^2=\lambda)\, }[/math]

(x; λ) approx f _ mathrm { normal }(x; mu = lambda，sigma ^ 2 = lambda) ，</math >

Variance-stabilizing transformation: If [math]\displaystyle{ X \sim \mathrm{Pois}(\lambda)\, }[/math], then

[math]\displaystyle{ Y = 2 \sqrt{X} \approx \mathcal{N}(2\sqrt{\lambda};1) }[/math],模板:R

[math]\displaystyle{ Y = 2 \sqrt{X} \approx \mathcal{N}(2\sqrt{\lambda};1) }[/math],

(2 sqrt { lambda } ; 1) </math > ,

and

及

[math]\displaystyle{ Y = \sqrt{X} \approx \mathcal{N}(\sqrt{\lambda};1/4) }[/math].模板:R

[math]\displaystyle{ Y = \sqrt{X} \approx \mathcal{N}(\sqrt{\lambda};1/4) }[/math].

(sqrt { lambda } ; 1/4) </math > .

Under this transformation, the convergence to normality (as [math]\displaystyle{ \lambda }[/math] increases) is far faster than the untransformed variable.^{[citation needed]} Other, slightly more complicated, variance stabilizing transformations are available,模板:R one of which is Anscombe transform.模板:R See Data transformation (statistics) for more general uses of transformations.

Under this transformation, the convergence to normality (as [math]\displaystyle{ \lambda }[/math] increases) is far faster than the untransformed variable. Other, slightly more complicated, variance stabilizing transformations are available, one of which is Anscombe transform. See Data transformation (statistics) for more general uses of transformations.

在这种转换下，收敛到正态的速度(如 < math > lambda </math > 增加)远远快于未转换的变量。还有一些稍微复杂一些的稳定方差的变换，其中之一就是安斯科姆变换。有关转换的更多一般用途，请参见数据转换(统计信息)。

If for every t > 0 the number of arrivals in the time interval [0, t] follows the Poisson distribution with mean λt, then the sequence of inter-arrival times are independent and identically distributed exponential random variables having mean 1/λ.模板:R

The cumulative distribution functions of the Poisson and chi-squared distributions are related in the following ways:模板:R

[math]\displaystyle{ F_\text{Poisson}(k;\lambda) = 1-F_{\chi^2}(2\lambda;2(k+1)) \quad\quad \text{ integer } k, }[/math]

1-F _ { chi ^ 2}(2 lambda; 2(k + 1)) quad text { integer } k，</math >

and模板:R

and

及

[math]\displaystyle{ \Pr(X=k)=F_{\chi^2}(2\lambda;2(k+1)) -F_{\chi^2}(2\lambda;2k) . \lt math\gt \Pr(X=k)=F_{\chi^2}(2\lambda;2(k+1)) -F_{\chi^2}(2\lambda;2k) . \lt math \gt Pr (x = k) = f { chi ^ 2}(2 lambda; 2(k + 1))-f { chi ^ 2}(2 lambda; 2k). }[/math]

</math>

数学

Poisson Approximation 泊松近似

Assume [math]\displaystyle{ X_1\sim\operatorname{Pois}(\lambda_1), X_2\sim\operatorname{Pois}(\lambda_2), \dots, X_n\sim\operatorname{Pois}(\lambda_n) }[/math] where [math]\displaystyle{ \lambda_1 + \lambda_2 + \dots + \lambda_n=1 }[/math], then^[3] [math]\displaystyle{ (X_1, X_2, \dots, X_n) }[/math] is multinomially distributed

Assume [math]\displaystyle{ X_1\sim\operatorname{Pois}(\lambda_1), X_2\sim\operatorname{Pois}(\lambda_2), \dots, X_n\sim\operatorname{Pois}(\lambda_n) }[/math] where [math]\displaystyle{ \lambda_1 + \lambda_2 + \dots + \lambda_n=1 }[/math], then [math]\displaystyle{ (X_1, X_2, \dots, X_n) }[/math] is multinomially distributed

假设 x _ 1 sim 操作者名为{ Pois }(lambda _ 1) ，x _ 2 sim 操作者名为{ Pois }(lambda _ 2) ，点，xn sim 操作者名为{ Pois }(lambda _ n) </math > 其中 < math > lambda _ 1 + lambda _ 2 + dots + lambda _ n = 1 </math 多项式 > ，那么 < math > (x _ 1，x _ 2，dots，x _ n) </math > 是统一分布的

[math]\displaystyle{ (X_1, X_2, \dots, X_n) \sim \operatorname{Mult}(N, \lambda_1, \lambda_2, \dots, \lambda_n) }[/math] conditioned on [math]\displaystyle{ N = X_1 + X_2 + \dots X_n }[/math].

(x _ 1，x _ 2，dots，x _ n) sim 操作员名称{ Mult }(n，λ _ 1，λ _ 2，dots，λ _ n) </math > 取决于 < math > n = x1 + x _ 2 + dots x _ n </math > 。

This means模板:R, among other things, that for any nonnegative function [math]\displaystyle{ f(x_1,x_2,\dots,x_n) }[/math],

This means, among other things, that for any nonnegative function [math]\displaystyle{ f(x_1,x_2,\dots,x_n) }[/math],

这意味着，对于任何非负函数 f (x _ 1，x _ 2，dots，x _ n) </math > ,

if [math]\displaystyle{ (Y_1, Y_2, \dots, Y_n)\sim\operatorname{Mult}(m, \mathbf{p}) }[/math] is multinomially distributed, then

如果[ math ](y _ 1，y _ 2，dots，y _ n) sim 操作符名称{ Mult }(m，mathbf { p }) </math > 是多项式分布，则

[math]\displaystyle{ \lt math\gt 《数学》 \operatorname{E}[f(Y_1, Y_2, \dots, Y_n)] \le e\sqrt{m}\operatorname{E}[f(X_1, X_2, \dots, X_n)] \operatorname{E}[f(Y_1, Y_2, \dots, Y_n)] \le e\sqrt{m}\operatorname{E}[f(X_1, X_2, \dots, X_n)] 操作员名称{ e }[ f (y _ 1，y _ 2，dots，y _ n)] le e sqrt { m }操作员名称{ e }[ f (x _ 1，x _ 2，dots，x _ n)] }[/math]

</math>

数学

where [math]\displaystyle{ (X_1, X_2, \dots, X_n)\sim\operatorname{Pois}(\mathbf{p}) }[/math].

其中 < math > (x _ 1，x _ 2，dots，x _ n) sim 操作员名称{ Pois }(mathbf { p }) </math > 。

The factor of [math]\displaystyle{ e\sqrt{m} }[/math] can be removed if [math]\displaystyle{ f }[/math] is further assumed to be monotonically increasing or decreasing.

如果进一步假定 < math > f </math > 是单调递增或递减的，则可以去掉 < math > e sqrt { m } </math > 的因子。

二元泊松分布Bivariate Poisson distribution

This distribution has been extended to the bivariate case.模板:R The generating function for this distribution is

This distribution has been extended to the bivariate case. The generating function for this distribution is

这种分布已经扩展到二元情况。这个分布的母函数是

[math]\displaystyle{ g( u, v ) = \exp[ ( \theta_1 - \theta_{12} )( u - 1 ) + ( \theta_2 - \theta_{12} )(v - 1) + \theta_{12} ( uv - 1 ) ] }[/math]

[math]\displaystyle{  g( u, v ) = \exp[ ( \theta_1 - \theta_{12} )( u - 1 ) + ( \theta_2 - \theta_{12} )(v - 1) + \theta_{12} ( uv - 1 ) ]  }[/math]

< math > g (u，v) = exp [(theta _ 1-theta _ {12})(u-1) + (theta _ 2-theta _ {12})(v-1) + theta _ {12}(uv-1)] </math >

with

与

[math]\displaystyle{ \theta_1, \theta_2 \gt \theta_{ 12 } \gt 0 \, }[/math]

[math]\displaystyle{  \theta_1, \theta_2 \gt  \theta_{ 12 } \gt  0 \,  }[/math]

1，theta 2，theta {12} > 0，</math >

The marginal distributions are Poisson(θ₁) and Poisson(θ₂) and the correlation coefficient is limited to the range

边缘分布为 Poisson ( 1 )和 Poisson ( 2 ) ，相关系数仅限于一定范围

[math]\displaystyle{ 0 \le \rho \le \min\left\{ \frac{ \theta_1 }{ \theta_2 }, \frac{ \theta_2 }{ \theta_1 } \right\} }[/math]

[math]\displaystyle{  0 \le \rho \le \min\left\{ \frac{ \theta_1 }{ \theta_2 }, \frac{ \theta_2 }{ \theta_1 } \right\} }[/math]

[数学][数学][数学][数学]

A simple way to generate a bivariate Poisson distribution [math]\displaystyle{ X_1,X_2 }[/math] is to take three independent Poisson distributions [math]\displaystyle{ Y_1,Y_2,Y_3 }[/math] with means [math]\displaystyle{ \lambda_1,\lambda_2,\lambda_3 }[/math] and then set [math]\displaystyle{ X_1 = Y_1 + Y_3,X_2 = Y_2 + Y_3 }[/math]. The probability function of the bivariate Poisson distribution is

一个简单的方法来产生一个二变量的泊松分布分布: 取3个独立的 Poisson 分布 < math > y _ 1，y _ 2，y _ 3 </math > ，用 < math > lambda _ 1，lambda _ 2，lambda _ 3 </math > 然后设置 < math > x _ 1 = y _ 1 + y _ 3，x _ 2 = y _ 2 + y _ 3 </math > 。二元概率密度函数变量的泊松分布变量是

 --fairywang(讨论)  【审校】“泊松分布分布”改为“泊松分布”，“泊松分布变量”改为“泊松分布变量”

[math]\displaystyle{ \lt math\gt 《数学》 \begin{align} \begin{align} 开始{ align } & \Pr(X_1=k_1,X_2=k_2) \\ & \Pr(X_1=k_1,X_2=k_2) \\ & Pr (x _ 1 = k _ 1，x _ 2 = k _ 2) = {} & \exp\left(-\lambda_1-\lambda_2-\lambda_3\right) \frac{\lambda_1^{k_1}}{k_1!} \frac{\lambda_2^{k_2}}{k_2!} \sum_{k=0}^{\min(k_1,k_2)} \binom{k_1}{k} \binom{k_2}{k} k! \left( \frac{\lambda_3}{\lambda_1\lambda_2}\right)^k = {} & \exp\left(-\lambda_1-\lambda_2-\lambda_3\right) \frac{\lambda_1^{k_1}}{k_1!} \frac{\lambda_2^{k_2}}{k_2!} \sum_{k=0}^{\min(k_1,k_2)} \binom{k_1}{k} \binom{k_2}{k} k! \left( \frac{\lambda_3}{\lambda_1\lambda_2}\right)^k = {} & exp left (- lambda _ 1-lambda _ 2-lambda _ 3 right) frac { lambda _ 1 ^ { k _ 1}{ k _ 1! }2 ^ { k2}{ k2! }{ k = 0} ^ { min (k _ 1，k _ 2)} binom { k _ 1}{ k } binom { k _ 2}{ k } ！左(frac { lambda _ 3}{ lambda _ 1 lambda _ 2}右) ^ k \end{align} \end{align} 结束{ align } }[/math]

</math>

数学

自由泊松分布Free Poisson distribution

The free Poisson distribution^[4] with jump size [math]\displaystyle{ \alpha }[/math] and rate [math]\displaystyle{ \lambda }[/math] arises in free probability theory as the limit of repeated free convolution

The free Poisson distribution with jump size [math]\displaystyle{ \alpha }[/math] and rate [math]\displaystyle{ \lambda }[/math] arises in free probability theory as the limit of repeated free convolution

带有跳跃大小 < math > alpha </math > 和速率 < math > lambda </math > 的 自由泊松分布Free Poisson distribution作为重复自由卷积的极限在自由概率论中出现

[math]\displaystyle{ \lt math\gt 《数学》 \left( \left(1-\frac{\lambda}{N}\right)\delta_0 + \frac{\lambda}{N}\delta_\alpha\right)^{\boxplus N} }[/math]

\left( \left(1-\frac{\lambda}{N}\right)\delta_0 + \frac{\lambda}{N}\delta_\alpha\right)^{\boxplus N}</math>

左(左(1-frac { lambda }{ n }右) delta _ 0 + frac { lambda }{ n } delta _ alpha 右) ^ { boxplus n } </math >

as N → ∞.

In other words, let [math]\displaystyle{ X_N }[/math] be random variables so that [math]\displaystyle{ X_N }[/math] has value [math]\displaystyle{ \alpha }[/math] with probability [math]\displaystyle{ \frac{\lambda}{N} }[/math] and value 0 with the remaining probability. Assume also that the family [math]\displaystyle{ X_1,X_2,\ldots }[/math] are freely independent. Then the limit as [math]\displaystyle{ N\to\infty }[/math] of the law of [math]\displaystyle{ X_1+\cdots +X_N }[/math]

换句话说，让 x _ n </math > 是随机变量，因此 x _ n </math > 具有值 < math > alpha </math > 具有概率 < math > frac { lambda }{ n } </math > ，值0具有剩余的概率。同时假设家庭成员 x1，x2，ldots </math > 是自由独立的。然后将极限值设为 < math > n，以确定 < math > x1 + cdots + xn </math > 的规律

 --fairywang(讨论)  【审校】“假设家庭成员 ”改为“假设集合 ”

is given by the Free Poisson law with parameters [math]\displaystyle{ \lambda,\alpha }[/math].

是由带参数的自由泊松定律给出的。

This definition is analogous to one of the ways in which the classical Poisson distribution is obtained from a (classical) Poisson process.

这个定义类似于从(经典)泊松过程获得经典 泊松分布Poisson distribution.的一种方法。

 --fairywang(讨论)  【审校】“泊松分布 ”改为“泊松分布 ”

The measure associated to the free Poisson law is given by^[5]

The measure associated to the free Poisson law is given by 与自由泊松定律相关的测度由以下给出

[math]\displaystyle{ \mu=\begin{cases} (1-\lambda) \delta_0 + \lambda \nu,& \text{if } 0\leq \lambda \leq 1 \\ \lt math\gt \mu=\begin{cases} (1-\lambda) \delta_0 + \lambda \nu,& \text{if } 0\leq \lambda \leq 1 \\ \lt math \gt mu = begin { cases }(1-lambda) delta _ 0 + lambda nu，& text { if }0 leq lambda leq 1 \nu, & \text{if }\lambda \gt 1, \nu, & \text{if }\lambda \gt 1, 1，& text { if } lambda \gt 1, \end{cases} \end{cases} 结束{ cases } }[/math]

</math>

数学

where

其中

[math]\displaystyle{ \nu = \frac{1}{2\pi\alpha t}\sqrt{4\lambda \alpha^2 - ( t - \alpha (1+\lambda))^2} \, dt }[/math]

[math]\displaystyle{ \nu = \frac{1}{2\pi\alpha t}\sqrt{4\lambda \alpha^2 - ( t - \alpha (1+\lambda))^2} \, dt }[/math]

4 lambda alpha ^ 2-(t-alpha (1 + lambda)) ^ 2} ，dt </math >

and has support [math]\displaystyle{ [\alpha (1-\sqrt{\lambda})^2,\alpha (1+\sqrt{\lambda})^2] }[/math].

并且支持 < math > [ alpha (1-sqrt { lambda }) ^ 2，alpha (1 + sqrt { lambda }) ^ 2] </math > 。

This law also arises in random matrix theory as the Marchenko–Pastur law. Its free cumulants are equal to [math]\displaystyle{ \kappa_n=\lambda\alpha^n }[/math].

这个定律也出现在随机矩阵理论中，称为马尔琴科-帕斯图定律。它的自由累积量等于 < math > kappa _ n = lambda alpha ^ n </math > 。

Some transforms of this law这一定律的一些变换

We give values of some important transforms of the free Poisson law; the computation can be found in e.g. in the book Lectures on the Combinatorics of Free Probability by A. Nica and R. Speicher^[6]

We give values of some important transforms of the free Poisson law; the computation can be found in e.g. in the book Lectures on the Combinatorics of Free Probability by A. Nica and R. Speicher

我们给出了自由泊松定律的一些重要变换的值。在 a. Nica 和 r. Speicher 合著的《自由概率组合学讲座》一书中

The R-transform of the free Poisson law is given by

以下给出自由泊松定律的 r- 变换

[math]\displaystyle{ R(z)=\frac{\lambda \alpha}{1-\alpha z}. }[/math]

[math]\displaystyle{ R(z)=\frac{\lambda \alpha}{1-\alpha z}.  }[/math]

1-alpha z }.数学

The Cauchy transform (which is the negative of the Stieltjes transformation) is given by

柯西变换(即 Stieltjes 变换的负变换)由以下给出

[math]\displaystyle{ \lt math\gt 《数学》 G(z) = \frac{ z + \alpha - \lambda \alpha - \sqrt{ (z-\alpha (1+\lambda))^2 - 4 \lambda \alpha^2}}{2\alpha z} G(z) = \frac{ z + \alpha - \lambda \alpha - \sqrt{ (z-\alpha (1+\lambda))^2 - 4 \lambda \alpha^2}}{2\alpha z} G (z) = frac { z + alpha-lambda alpha-sqrt {(z-alpha (1 + lambda)))) ^ 2-4 lambda alpha ^ 2}{2 alpha z } }[/math]

</math>

数学

The S-transform is given by

以下给出了 s 变换的一般形式

[math]\displaystyle{ \lt math\gt 《数学》 S(z) = \frac{1}{z+\lambda} S(z) = \frac{1}{z+\lambda} (z) = frac {1}{ z + lambda } }[/math]

</math>

数学

in the case that [math]\displaystyle{ \alpha=1 }[/math].

在这种情况下。

Statistical Inference 统计学推论

模板:又见

Parameter estimation参数估计

Given a sample of n measured values [math]\displaystyle{ k_i \in \{0,1,...\} }[/math], for i = 1, ..., n, we wish to estimate the value of the parameter λ of the Poisson population from which the sample was drawn. The maximum likelihood estimate is ^[7]

Given a sample of n measured values [math]\displaystyle{ k_i \in \{0,1,...\} }[/math], for i = 1, ..., n, we wish to estimate the value of the parameter λ of the Poisson population from which the sample was drawn. The maximum likelihood estimate is

给定一个 n 个测量值的样本{0,1，... } </math > ，对于 i = 1，... ，n，我们希望估计取样的泊松总体参数的值。 最大似然估计The maximum likelihood estimate是

[math]\displaystyle{ \widehat{\lambda}_\mathrm{MLE}=\frac{1}{n}\sum_{i=1}^n k_i. \! }[/math]

[math]\displaystyle{ \widehat{\lambda}_\mathrm{MLE}=\frac{1}{n}\sum_{i=1}^n k_i. \! }[/math]

1}{ n } sum { i = 1} ^ n ki.! 数学

Since each observation has expectation λ so does the sample mean. Therefore, the maximum likelihood estimate is an unbiased estimator of λ. It is also an efficient estimator since its variance achieves the Cramér–Rao lower bound (CRLB).^{[citation needed]} Hence it is minimum-variance unbiased. Also it can be proven that the sum (and hence the sample mean as it is a one-to-one function of the sum) is a complete and sufficient statistic for λ.

Since each observation has expectation λ so does the sample mean. Therefore, the maximum likelihood estimate is an unbiased estimator of λ. It is also an efficient estimator since its variance achieves the Cramér–Rao lower bound (CRLB). Hence it is minimum-variance unbiased. Also it can be proven that the sum (and hence the sample mean as it is a one-to-one function of the sum) is a complete and sufficient statistic for λ.

因为每个观测值都有期望值，所以样本的意义也是如此。因此， 最大似然估计The maximum likelihood estimate是。由于其方差达到了 CRLB 下界，因此它也是一个有效的估计量。它是最小方差无偏的。也可以证明和(因此样本平均值是和的单射)是一个完整充分的统计量。

To prove sufficiency we may use the factorization theorem. Consider partitioning the probability mass function of the joint Poisson distribution for the sample into two parts: one that depends solely on the sample [math]\displaystyle{ \mathbf{x} }[/math] (called [math]\displaystyle{ h(\mathbf{x}) }[/math]) and one that depends on the parameter [math]\displaystyle{ \lambda }[/math] and the sample [math]\displaystyle{ \mathbf{x} }[/math] only through the function [math]\displaystyle{ T(\mathbf{x}) }[/math]. Then [math]\displaystyle{ T(\mathbf{x}) }[/math] is a sufficient statistic for [math]\displaystyle{ \lambda }[/math].

为了证明充分性，我们可以用 因子分解定理Factorization theorem。考虑将 联合泊松分布Joint Poisson distribution的 概率质量函数Probability mass function分成两部分: 一部分仅依赖于样本 < math > mathbf { x } </math > (称为 < math > h (mathbf { x }) </math >) ，另一部分依赖于参数 < math > lambda </math > 和样本 < math > mathbf { x } </math > 只通过函数 math < t (mathbf { x }) </math > 。那么 < math > t (mathbf { x }) </math > 就是 < math > lambda </math > 的一个充分的统计量。

[math]\displaystyle{ P(\mathbf{x})=\prod_{i=1}^n\frac{\lambda^{x_i} e^{-\lambda}}{x_i!}=\frac{1}{\prod_{i=1}^n x_i!} \times \lambda^{\sum_{i=1}^n x_i}e^{-n\lambda} }[/math]

[math]\displaystyle{  P(\mathbf{x})=\prod_{i=1}^n\frac{\lambda^{x_i} e^{-\lambda}}{x_i!}=\frac{1}{\prod_{i=1}^n x_i!} \times \lambda^{\sum_{i=1}^n x_i}e^{-n\lambda}  }[/math]

= prod _ { i = 1} ^ n frac { lambda ^ { x _ i } e ^ {-lambda }{ x _ i！1}{ prod { i = 1} ^ n x i! }乘以 lambda ^ { sum { i = 1} ^ n xi } e ^ {-n lambda } </math >

The first term, [math]\displaystyle{ h(\mathbf{x}) }[/math], depends only on [math]\displaystyle{ \mathbf{x} }[/math]. The second term, [math]\displaystyle{ g(T(\mathbf{x})|\lambda) }[/math], depends on the sample only through [math]\displaystyle{ T(\mathbf{x})=\sum_{i=1}^nx_i }[/math]. Thus, [math]\displaystyle{ T(\mathbf{x}) }[/math] is sufficient.

第一个术语，< math > h (mathbf { x }) </math > ，仅依赖于 < math > mathbf { x } </math > 。第二个术语，< math > g (t (mathbf { x }) | lambda) </math > ，仅通过 < math > t (mathbf { x }) = sum { i = 1} ^ nx _ i </math > 取决于样本。因此，< math > t (mathbf { x }) </math > 就足够了。

To find the parameter λ that maximizes the probability function for the Poisson population, we can use the logarithm of the likelihood function:

为了找到泊松族群概率密度函数最大的参数λ ，我们可以使用 似然函数Likelihood function的对数:

[math]\displaystyle{ \begin{align} \ell(\lambda) & = \ln \prod_{i=1}^n f(k_i \mid \lambda) \\ & = \sum_{i=1}^n \ln\!\left(\frac{e^{-\lambda}\lambda^{k_i}}{k_i!}\right) \\ & = -n\lambda + \left(\sum_{i=1}^n k_i\right) \ln(\lambda) - \sum_{i=1}^n \ln(k_i!). \end{align} }[/math]

[math]\displaystyle{  \begin{align} \ell(\lambda) & = \ln \prod_{i=1}^n f(k_i \mid \lambda) \\ & = \sum_{i=1}^n \ln\!\left(\frac{e^{-\lambda}\lambda^{k_i}}{k_i!}\right) \\ & = -n\lambda + \left(\sum_{i=1}^n k_i\right) \ln(\lambda) - \sum_{i=1}^n \ln(k_i!). \end{align}  }[/math]

{ align } ell (lambda) & = ln prod { i = 1} ^ n f (k _ i mid lambda) & = sum { i = 1} ^ n ln! left (frac { e ^ {-lambda } lambda ^ { k _ i }{ k _ i！} right) & =-n lambda + left (sum _ { i = 1} ^ n k _ i right) ln (lambda)-sum _ { i = 1} ^ n ln (k _ i!).结束{ align } </math >

We take the derivative of [math]\displaystyle{ \ell }[/math] with respect to λ and compare it to zero:

We take the derivative of [math]\displaystyle{ \ell }[/math] with respect to λ and compare it to zero:

我们对 < math > 求导，然后将其与零进行比较:

[math]\displaystyle{ \frac{\mathrm{d}}{\mathrm{d}\lambda} \ell(\lambda) = 0 \iff -n + \left(\sum_{i=1}^n k_i\right) \frac{1}{\lambda} = 0. \! }[/math]

[math]\displaystyle{ \frac{\mathrm{d}}{\mathrm{d}\lambda} \ell(\lambda) = 0 \iff -n + \left(\sum_{i=1}^n k_i\right) \frac{1}{\lambda} = 0. \! }[/math]

1}{ lambda } = 0 iff-n + left (sum { i = 1} ^ n k i right) frac {1}{ lambda } = 0.! 数学

Solving for λ gives a stationary point.

解出 λ得到 驻点Stationary point。

[math]\displaystyle{ \lambda = \frac{\sum_{i=1}^n k_i}{n} }[/math]

[math]\displaystyle{  \lambda = \frac{\sum_{i=1}^n k_i}{n} }[/math]

{ math > lambda = frac { sum { i = 1} ^ n k _ i }{ n } </math >

So λ is the average of the k_i values. Obtaining the sign of the second derivative of L at the stationary point will determine what kind of extreme value λ is.

K i 值的平均值也是如此。在驻点得到 l 的二阶导数的符号将决定什么是极值。

[math]\displaystyle{ \frac{\partial^2 \ell}{\partial \lambda^2} = -\lambda^{-2}\sum_{i=1}^n k_i }[/math]

[math]\displaystyle{ \frac{\partial^2 \ell}{\partial \lambda^2} = -\lambda^{-2}\sum_{i=1}^n k_i  }[/math]

{ partial ^ 2 ell }{ partial lambda ^ 2} =-lambda ^ {-2} sum { i = 1} ^ n k i </math >

Evaluating the second derivative at the stationary point gives:

Evaluating the second derivative at the stationary point gives:

在驻点对二阶导数进行评估得出:

[math]\displaystyle{ \frac{\partial^2 \ell}{\partial \lambda^2} = - \frac{n^2}{\sum_{i=1}^n k_i} }[/math]

[math]\displaystyle{ \frac{\partial^2 \ell}{\partial \lambda^2} = - \frac{n^2}{\sum_{i=1}^n k_i}  }[/math]

{ partial ^ 2 ell }{ partial lambda ^ 2} =-frac { n ^ 2}{ sum { i = 1} ^ n ki } </math >

which is the negative of n times the reciprocal of the average of the k_i. This expression is negative when the average is positive. If this is satisfied, then the stationary point maximizes the probability function.

它是 n 乘以 k i 平均值的倒数。当平均数为正时，这个表达式是负的。如果这一点得到了满足，那么 驻点The stationary point最大化了概率密度函数。

For completeness, a family of distributions is said to be complete if and only if [math]\displaystyle{ E(g(T)) = 0 }[/math] implies that [math]\displaystyle{ P_\lambda(g(T) = 0) = 1 }[/math] for all [math]\displaystyle{ \lambda }[/math]. If the individual [math]\displaystyle{ X_i }[/math] are iid [math]\displaystyle{ \mathrm{Po}(\lambda) }[/math], then [math]\displaystyle{ T(\mathbf{x})=\sum_{i=1}^nX_i\sim \mathrm{Po}(n\lambda) }[/math]. Knowing the distribution we want to investigate, it is easy to see that the statistic is complete.

为了完整性起见，一个分布族被认为是完整的，当且仅当 < math > e (g (t)) = 0 </math > 意味着 < math > p lambda (g (t) = 0) = 1 </math > 对于所有 < math > λ </math > 。如果个体 < math > xi </math > 是 < math > mathrm { Po }(λ) </math > ，那么 < math > t (mathbf { x }) = sum { i = 1} ^ nX _ i sim mathrm { Po }(n lambda) </math > 。了解了我们要调查的分布情况后，很容易看出统计数据是完整的。

[math]\displaystyle{ E(g(T))=\sum_{t=0}^\infty g(t)\frac{(n\lambda)^te^{-n\lambda}}{t!}=0 }[/math]

[math]\displaystyle{ E(g(T))=\sum_{t=0}^\infty g(t)\frac{(n\lambda)^te^{-n\lambda}}{t!}=0 }[/math]

< math > e (g (t)) = sum { t = 0} ^ infty g (t) frac {(n lambda) ^ te ^ {-n lambda }{ t！0 </math >

For this equality to hold, [math]\displaystyle{ g(t) }[/math] must be 0. This follows from the fact that none of the other terms will be 0 for all [math]\displaystyle{ t }[/math] in the sum and for all possible values of [math]\displaystyle{ \lambda }[/math]. Hence, [math]\displaystyle{ E(g(T)) = 0 }[/math] for all [math]\displaystyle{ \lambda }[/math] implies that [math]\displaystyle{ P_\lambda(g(T) = 0) = 1 }[/math], and the statistic has been shown to be complete.

要保证这个等式成立，< math > g (t) </math > 必须为0。这源于这样一个事实: 对于所有 < math > t </math > 的和和以及 < math > > lambda </math > 的所有可能值，其他项都不会为0。因此，e (g (t)) = 0 </math > > lambda </math > 意味着 < math > p _ lambda (g (t) = 0 = 1 </math > ，统计已被证明是完整的。

Confidence interval 置信区间Confidence interval

The confidence interval for the mean of a Poisson distribution can be expressed using the relationship between the cumulative distribution functions of the Poisson and chi-squared distributions. The chi-squared distribution is itself closely related to the gamma distribution, and this leads to an alternative expression. Given an observation k from a Poisson distribution with mean μ, a confidence interval for μ with confidence level $1 - α$ is

The confidence interval for the mean of a Poisson distribution can be expressed using the relationship between the cumulative distribution functions of the Poisson and chi-squared distributions. The chi-squared distribution is itself closely related to the gamma distribution, and this leads to an alternative expression. Given an observation k from a Poisson distribution with mean μ, a confidence interval for μ with confidence level is

置信区间Confidence interval 的平均 泊松分布Poisson distribution可以用泊松分布和卡方分布的累积分布函数之间的关系来表示。卡方分布本身与伽玛分布密切相关，这导致了另一种表达方式。给定一个来自平均泊松分布的观测值 k，一个带有置信水平的置信区间是

 --fairywang(讨论)  【审校】“泊松分布 ”改为“泊松分布 ”

[math]\displaystyle{ \tfrac 12\chi^{2}(\alpha/2; 2k) \le \mu \le \tfrac 12 \chi^{2}(1-\alpha/2; 2k+2), }[/math]

12 chi ^ {2}(alpha/2; 2k) le mu le tfrac 12 chi ^ {2}(1-alpha/2; 2k + 2) ，</math >

or equivalently,

或者等价,

[math]\displaystyle{ F^{-1}(\alpha/2; k,1) \le \mu \le F^{-1}(1-\alpha/2; k+1,1), }[/math]

(1-alpha/2; k，1) le mu le f ^ {-1}(1-alpha/2; k + 1,1) ，</math >

where [math]\displaystyle{ \chi^{2}(p;n) }[/math] is the quantile function (corresponding to a lower tail area p) of the chi-squared distribution with n degrees of freedom and [math]\displaystyle{ F^{-1}(p;n,1) }[/math] is the quantile function of a gamma distribution with shape parameter n and scale parameter 1.模板:R This interval is 'exact' in the sense that its coverage probability is never less than the nominal $1 - α$ .

where [math]\displaystyle{ \chi^{2}(p;n) }[/math] is the quantile function (corresponding to a lower tail area p) of the chi-squared distribution with n degrees of freedom and [math]\displaystyle{ F^{-1}(p;n,1) }[/math] is the quantile function of a gamma distribution with shape parameter n and scale parameter 1. This interval is 'exact' in the sense that its coverage probability is never less than the nominal .

其中 < math > chi ^ {2}(p; n) </math > 是 n 个自由度的分位函数，< math > f ^ {-1}(p; n，1) </math > 是形状参数 n 和尺度参数1的卡方分布的分位函数。这个时间间隔是“精确的” ，因为它的覆盖概率从来没有小于名义值。

When quantiles of the gamma distribution are not available, an accurate approximation to this exact interval has been proposed (based on the Wilson–Hilferty transformation):模板:R

When quantiles of the gamma distribution are not available, an accurate approximation to this exact interval has been proposed (based on the Wilson–Hilferty transformation):

当伽玛分布的分位数不可用时，对这个精确区间提出了精确的近似(基于 Wilson-Hilferty 变换) :

[math]\displaystyle{ k \left( 1 - \frac{1}{9k} - \frac{z_{\alpha/2}}{3\sqrt{k}}\right)^3 \le \mu \le (k+1) \left( 1 - \frac{1}{9(k+1)} + \frac{z_{\alpha/2}}{3\sqrt{k+1}}\right)^3, }[/math]

< math > k left (1-frac {1}{9k }-frac { z _ { alpha/2}{3 sqrt { k }右) ^ 3 le mu le (k + 1) left (1-frac {1}{9(k + 1)}} + frac { z _ { alpha/2}{3 sqrt { k + 1}右) ^ 3，</math >

where [math]\displaystyle{ z_{\alpha/2} }[/math] denotes the standard normal deviate with upper tail area $α / 2$ .

where [math]\displaystyle{ z_{\alpha/2} }[/math] denotes the standard normal deviate with upper tail area .

其中 < math > z _ { alpha/2} </math > 表示标准的正常偏差和上尾区。

For application of these formulae in the same context as above (given a sample of n measured values k_i each drawn from a Poisson distribution with mean λ), one would set

为了在与上述相同的上下文中应用这些公式(给定一个 n 个测量值 k i 每个取自一个泊松分布的平均值) ，我们将设置

 --fairywang(讨论)  【审校】“泊松分布 ”改为“泊松分布 ”

[math]\displaystyle{ k=\sum_{i=1}^n k_i ,\! }[/math]

[ math > k = sum { i = 1} ^ n k _ i，

calculate an interval for μ = nλ, and then derive the interval for λ.

计算 = n 的区间，然后推导出。

Bayesian inference 贝叶斯推理

In Bayesian inference, the conjugate prior for the rate parameter λ of the Poisson distribution is the gamma distribution.模板:R Let

In Bayesian inference, the conjugate prior for the rate parameter λ of the Poisson distribution is the gamma distribution. Let

在 Bayesian inference 贝叶斯推理中，泊松分布的速率参数的 共轭先验Conjugate prior是伽玛分布。让

 --fairywang(讨论)  【审校】“泊松分布 ”改为“泊松分布 ”

[math]\displaystyle{ \lambda \sim \mathrm{Gamma}(\alpha, \beta) \! }[/math]

{ Gamma }(alpha，beta)

denote that λ is distributed according to the gamma density g parameterized in terms of a shape parameter α and an inverse scale parameter β:

表示根据以形状参数和反比例尺参数表示的伽马密度 g 分布:

[math]\displaystyle{ g(\lambda \mid \alpha,\beta) = \frac{\beta^{\alpha}}{\Gamma(\alpha)} \; \lambda^{\alpha-1} \; e^{-\beta\,\lambda} \qquad \text{ for } \lambda\gt 0 \,\!. }[/math]

G (lambda mid alpha，beta) = frac { beta ^ { alpha }{ Gamma (alpha)} ; lambda ^ { alpha-1} ; e ^ {-beta，lambda } qquad text { for } lambda > 0，! </math >

Then, given the same sample of n measured values k_i as before, and a prior of Gamma(α, β), the posterior distribution is

然后，给定相同的样本 n 测量值 k i 和之前的 Gamma (,) ，后验概率是

[math]\displaystyle{ \lambda \sim \mathrm{Gamma}\left(\alpha + \sum_{i=1}^n k_i, \beta + n\right). \! }[/math]

左(alpha + sum _ { i = 1} ^ n k _ i，beta + n right)。! 数学

The posterior mean E[λ] approaches the maximum likelihood estimate [math]\displaystyle{ \widehat{\lambda}_\mathrm{MLE} }[/math] in the limit as [math]\displaystyle{ \alpha\to 0,\ \beta\to 0 }[/math], which follows immediately from the general expression of the mean of the gamma distribution.

后验平均值 e []接近极限中的最大似然估计 < math > lambda } _ mathrm { MLE } </math > ，它紧跟在伽玛分布平均值的一般表达式之后。

The posterior predictive distribution for a single additional observation is a negative binomial distribution,模板:R sometimes called a gamma–Poisson distribution.

The posterior predictive distribution for a single additional observation is a negative binomial distribution, sometimes called a gamma–Poisson distribution.

单一额外观察的后验预测分布是负二项分布，有时称为泊松分布。

 --fairywang(讨论)  【审校】“泊松分布 ”改为“泊松分布 ”

Simultaneous estimation of multiple Poisson means 多重泊松均值的同步估计

Suppose [math]\displaystyle{ X_1, X_2, \dots, X_p }[/math] is a set of independent random variables from a set of [math]\displaystyle{ p }[/math] Poisson distributions, each with a parameter [math]\displaystyle{ \lambda_i }[/math], [math]\displaystyle{ i=1,\dots,p }[/math], and we would like to estimate these parameters. Then, Clevenson and Zidek show that under the normalized squared error loss [math]\displaystyle{ L(\lambda,{\hat \lambda})=\sum_{i=1}^p \lambda_i^{-1} ({\hat \lambda}_i-\lambda_i)^2 }[/math], when [math]\displaystyle{ p\gt 1 }[/math], then, similar as in Stein's example for the Normal means, the MLE estimator [math]\displaystyle{ {\hat \lambda}_i = X_i }[/math] is inadmissible. 模板:R

Suppose [math]\displaystyle{ X_1, X_2, \dots, X_p }[/math] is a set of independent random variables from a set of [math]\displaystyle{ p }[/math] Poisson distributions, each with a parameter [math]\displaystyle{ \lambda_i }[/math], [math]\displaystyle{ i=1,\dots,p }[/math], and we would like to estimate these parameters. Then, Clevenson and Zidek show that under the normalized squared error loss [math]\displaystyle{ L(\lambda,{\hat \lambda})=\sum_{i=1}^p \lambda_i^{-1} ({\hat \lambda}_i-\lambda_i)^2 }[/math], when [math]\displaystyle{ p\gt 1 }[/math], then, similar as in Stein's example for the Normal means, the MLE estimator [math]\displaystyle{ {\hat \lambda}_i = X_i }[/math] is inadmissible.

假设 x _ 1，x _ 2，点，x _ p </math > 是一组来自一组 p </math > 泊松分布的独立随机变量，每个分布都有一个参数 λ < math > i </math > ，< math > i = 1，点，p </math > ，我们想估计这些参数。然后，clevensen 和 Zidek 证明，在归一化的平方误差损失 < math > l (lambda，{ hat lambda }) = sum { i = 1} ^ p lambda i ^ {-1}({ hat lambda } i-lambda _ i) ^ 2 </math > 下，当 < math > p > 1 </math > ，那么，类似于 Stein 的例子中的正态方法，MLE < math > lambda } i = xi </math > 是不允许的。

In this case, a family of minimax estimators is given for any [math]\displaystyle{ 0 \lt c \leq 2(p-1) }[/math] and [math]\displaystyle{ b \geq (p-2+p^{-1}) }[/math] as模板:R

In this case, a family of minimax estimators is given for any [math]\displaystyle{ 0 \lt c \leq 2(p-1) }[/math] and [math]\displaystyle{ b \geq (p-2+p^{-1}) }[/math] as

在这种情况下，对于任意 < math > 0 < c leq 2(p-1) </math > 和 < math > b geq (p-2 + p ^ {-1}) </math > ，给出了极大极小估计族

[math]\displaystyle{ {\hat \lambda}_i = \left(1 - \frac{c}{b + \sum_{i=1}^p X_i}\right) X_i, \qquad i=1,\dots,p. }[/math]

{ hat lambda } _ i = left (1-frac { c }{ b + sum { i = 1} ^ p x _ i } right) xi，qquad i = 1，dots，p </math >

Occurrence and applications 发生与应用

模板:More citations needed

Applications of the Poisson distribution can be found in many fields including:模板:R

Applications of the Poisson distribution can be found in many fields including:

泊松分布Poisson distribution可以应用在很多领域，包括:

 --fairywang(讨论)  【审校】“泊松分布”改为“泊松分布”

Telecommunication example: telephone calls arriving in a system.
电信示例：到达系统的电话。

 --fairywang(讨论)  【审校】“到达系统的电话”改为“一个系统中的来电数 ”

Astronomy example: photons arriving at a telescope.
天文学例子：到达望远镜的光子。
Chemistry example: the molar mass distribution of a living polymerization.模板:R
化学示例：一种[[活性聚合物]的摩尔质量分布。
Biology example: the number of mutations on a strand of DNA per unit length.
生物示例：每单位DNA链上的突变数。
Management example: customers arriving at a counter or call centre.
管理示例：到达柜台或呼叫中心的客户。
Finance and insurance example: number of losses or claims occurring in a given period of time.
金融和保险示例：在一定时期内发生的损失或索赔的数量。
Earthquake seismology example: an asymptotic Poisson model of seismic risk for large earthquakes.模板:R
地震地震学实例：大地震地震危险性的渐近泊松模型。模板:R
Radioactivity example: number of decays in a given time interval in a radioactive sample.
放射性示例：在放射性样本中给定时间间隔内的衰变次数。
Optics example: the number of photons emitted in a single laser pulse. This is a major vulnerability to most Quantum key distribution protocols known as Photon Number Splitting (PNS).
光学示例：单个激光脉冲中发射的光子数。这是大多数量子密钥分发协议的主要漏洞，被称为光子数分裂（PNS）。

The Poisson distribution arises in connection with Poisson processes. It applies to various phenomena of discrete properties (that is, those that may happen 0, 1, 2, 3, ... times during a given period of time or in a given area) whenever the probability of the phenomenon happening is constant in time or space. Examples of events that may be modelled as a Poisson distribution include:

泊松分布过程与泊松过程有关。它适用于各种离散性质的现象(也就是说，那些可能发生0,1,2,3，... 在给定时间内或在给定区域) ，只要现象发生的概率在时间或空间上是常数。可以被模仿为泊松分布的活动包括:

 --fairywang(讨论)  【审校】“泊松分布”改为“泊松分布”

-->

-->

The number of soldiers killed by horse-kicks each year in each corps in the Prussian cavalry. This example was used in a book by Ladislaus Bortkiewicz (1868–1931).模板:R
各兵团每年死于马踢的士兵人数。这个例子在[[Ladislaus Bortkiewicz]的一本书中使用过(1868–1931).模板:R。
The number of yeast cells used when brewing Guinness beer. This example was used by William Sealy Gosset (1876–1937).模板:R 模板:R
酿造吉尼斯啤酒时使用的酵母细胞数量。这个例子被William sely Gosset（1876-1937）使用。模板:R 模板:R
The number of phone calls arriving at a call centre within a minute. This example was described by A.K. Erlang (1878–1929).模板:R
一分钟内到达呼叫中心的电话数。这个例子由 A.K.Erlang（1878-1929）描述模板:R。
Internet traffic.
互联网堵塞。
The number of goals in sports involving two competing teams.模板:R
两支参赛队伍在运动中的进球数。模板:R
The number of deaths per year in a given age group.
特定年龄组每年的死亡人数。
The number of jumps in a stock price in a given time interval.
股票价格在给定时间间隔内的波动次数。
Under an assumption of homogeneity, the number of times a web server is accessed per minute.
在[[泊松过程#齐次|均匀性]假设下，每分钟访问web服务器的次数。
The number of mutations in a given stretch of DNA after a certain amount of radiation.
在一定量的辐射之后，在给定的DNA段中突变的数目。
The proportion of cells that will be infected at a given multiplicity of infection.
在给定的时间内被感染的细胞的比例。
The number of bacteria in a certain amount of liquid.模板:R
一定量液体中细菌的数量。模板:R
The arrival of photons on a pixel circuit at a given illumination and over a given time period.
在给定的光照和时间间隔，到达像素电路的光子。
The targeting of V-1 flying bombs on London during World War II investigated by R. D. Clarke in 1946.模板:R
二战期间伦敦对V-1飞弹的目标调查||由R. D. Clarke 1946年调查。模板:R

Gallagher showed in 1976 that the counts of prime numbers in short intervals obey a Poisson distribution模板:R provided a certain version of the unproved prime r-tuple conjecture of Hardy-Littlewood 模板:R is true.

Gallagher showed in 1976 that the counts of prime numbers in short intervals obey a Poisson distribution provided a certain version of the unproved prime r-tuple conjecture of Hardy-Littlewood is true.

1976年，加拉格尔指出，只要Hardy-Littlewo素数r-元组猜想的一个版本为正确，短时间间隔内质数的计数即服从泊松分布。

模板:Anchor

Law of rare events稀有事件定律

文件:Binomial versus poisson.svg

Comparison of the Poisson distribution (black lines) and the binomial distribution with n = 10 (red circles), n = 20 (blue circles), n = 1000 (green circles). All distributions have a mean of 5. The horizontal axis shows the number of events k. As n gets larger, the Poisson distribution becomes an increasingly better approximation for the binomial distribution with the same mean.

Comparison of the Poisson distribution (black lines) and the [[binomial distribution with n = 10 (red circles), n = 20 (blue circles), n = 1000 (green circles). All distributions have a mean of 5. The horizontal axis shows the number of events k. As n gets larger, the Poisson distribution becomes an increasingly better approximation for the binomial distribution with the same mean.]]

泊松分布(黑线)与[二项分布(红圈) ，n = 20(蓝圈) ，n = 1000(绿圈)的比较。所有分布的平均值都是5。水平轴显示事件的数量 k。随着 n 变得越来越大，泊松分布变成了一个越来越好的平均二项分布。]

 --fairywang(讨论)  【审校】“泊松分布”改为“泊松分布”

The rate of an event is related to the probability of an event occurring in some small subinterval (of time, space or otherwise). In the case of the Poisson distribution, one assumes that there exists a small enough subinterval for which the probability of an event occurring twice is "negligible". With this assumption one can derive the Poisson distribution from the Binomial one, given only the information of expected number of total events in the whole interval. Let this total number be [math]\displaystyle{ \lambda }[/math]. Divide the whole interval into [math]\displaystyle{ n }[/math] subintervals [math]\displaystyle{ I_1,\dots,I_n }[/math] of equal size, such that [math]\displaystyle{ n }[/math] > [math]\displaystyle{ \lambda }[/math] (since we are interested in only very small portions of the interval this assumption is meaningful). This means that the expected number of events in an interval [math]\displaystyle{ I_i }[/math] for each [math]\displaystyle{ i }[/math] is equal to [math]\displaystyle{ \lambda/n }[/math]. Now we assume that the occurrence of an event in the whole interval can be seen as a Bernoulli trial, where the [math]\displaystyle{ i^{th} }[/math] trial corresponds to looking whether an event happens at the subinterval [math]\displaystyle{ I_i }[/math] with probability [math]\displaystyle{ \lambda/n }[/math]. The expected number of total events in [math]\displaystyle{ n }[/math] such trials would be [math]\displaystyle{ \lambda }[/math], the expected number of total events in the whole interval. Hence for each subdivision of the interval we have approximated the occurrence of the event as a Bernoulli process of the form [math]\displaystyle{ \textrm{B}(n,\lambda/n) }[/math]. As we have noted before we want to consider only very small subintervals. Therefore, we take the limit as [math]\displaystyle{ n }[/math] goes to infinity.

事件的发生率与事件发生在某个小的子间隔(时间、空间或其他)的概率有关。在泊松分布的例子中，我们假设存在一个足够小的子区间，其中一个事件发生两次的概率是“可以忽略的”。有了这个假设，我们就可以从二项式中推导出泊松分布，只需要给出整个时间间隔内预期的事件总数的信息。设这个总数是 < math > > lambda </math > 。将整个区间分为 < math > n </math > 子区间 < math > i _ 1，点，i _ n </math > 大小相等，这样 < math > n </math > < math > lambda </math > (因为我们只对区间的很小一部分感兴趣，所以这个假设是有意义的)。这意味着每个 < math > i </math > 中期望的事件数等于 < math > lambda/n </math > 。现在，我们假设一个事件在整个时间间隔内的发生可以被看作是伯努利试验，其中，“ math”试验对应于观察一个事件是否在子时间间隔内发生。在 < math > n </math > 这样的试验中预期的总事件数是 < math > lambda </math > ，这是整个间隔中预期的总事件数。因此，对于区间的每一个细分，我们都近似地将事件的发生作为形式 < math > textrm { b }(n，lambda/n) </math > 的伯努利过程。正如我们之前指出的，我们只想考虑非常小的子区间。因此，我们将极限取为 < math > n </math > 到无穷大。

 --fairywang(讨论)  【审校】“泊松分布”改为“泊松分布”

In this case the binomial distribution converges to what is known as the Poisson distribution by the Poisson limit theorem.

在这种情况下，二项分布收敛于泊松极限定理所称的泊松分布。

 --fairywang(讨论)  【审校】“泊松分布”改为“泊松分布”

In several of the above examples—such as, the number of mutations in a given sequence of DNA—the events being counted are actually the outcomes of discrete trials, and would more precisely be modelled using the binomial distribution, that is

在上面的几个例子中---- 例如，一个给定序列的 dna 突变的数量---- 被计算的事件实际上是离散试验的结果，也就是说，更准确地说，是用二项分布模型来模拟的

[math]\displaystyle{ X \sim \textrm{B}(n,p). \, }[/math]

X sim textrm { b }(n，p).，math

In such cases n is very large and p is very small (and so the expectation np is of intermediate magnitude). Then the distribution may be approximated by the less cumbersome Poisson distribution^{[citation needed]}

In such cases n is very large and p is very small (and so the expectation np is of intermediate magnitude). Then the distribution may be approximated by the less cumbersome Poisson distribution

在这种情况下，n 是非常大的，p 是非常小的(所以期望 np 是中等大小)。然后，分布可以近似于不那么麻烦的泊松分布

 --fairywang(讨论)  【审校】“泊松分布”改为“泊松分布”

[math]\displaystyle{ X \sim \textrm{Pois}(np). \, }[/math]

[math]\displaystyle{ X \sim \textrm{Pois}(np).，math This approximation is sometimes known as the ''law of rare events'',{{r|Cameron1998|p=5}}since each of the ''n'' individual [[Bernoulli distribution|Bernoulli events]] rarely occurs. The name may be misleading because the total count of success events in a Poisson process need not be rare if the parameter ''np'' is not small. For example, the number of telephone calls to a busy switchboard in one hour follows a Poisson distribution with the events appearing frequent to the operator, but they are rare from the point of view of the average member of the population who is very unlikely to make a call to that switchboard in that hour. This approximation is sometimes known as the law of rare events,since each of the n individual Bernoulli events rarely occurs. The name may be misleading because the total count of success events in a Poisson process need not be rare if the parameter np is not small. For example, the number of telephone calls to a busy switchboard in one hour follows a Poisson distribution with the events appearing frequent to the operator, but they are rare from the point of view of the average member of the population who is very unlikely to make a call to that switchboard in that hour. 这种近似有时被称为稀有事件定律，因为 n 个伯努利事件中的每一个很少发生。这个名称可能有误导性，因为如果参数 np 不小，那么 Poisson 过程中成功事件的总计数就不会很少。例如，一个小时内打给忙碌总机的电话数量跟随着一个泊松分布，这些事件在接线员看来是频繁的，但是从普通人的角度来看，这些事件很少发生，因为他们不太可能在那个小时内打电话给总机。 --[[用户:fairywang|fairywang]]([[用户讨论:fairywang|讨论]]) 【审校】“泊松分布”改为“泊松分布” The word ''law'' is sometimes used as a synonym of [[probability distribution]], and ''convergence in law'' means ''convergence in distribution''. Accordingly, the Poisson distribution is sometimes called the "law of small numbers" because it is the probability distribution of the number of occurrences of an event that happens rarely but has very many opportunities to happen. ''The Law of Small Numbers'' is a book by Ladislaus Bortkiewicz about the Poisson distribution, published in 1898.{{r|vonBortkiewitsch1898}}{{r|Edgeworth1913}} The word law is sometimes used as a synonym of probability distribution, and convergence in law means convergence in distribution. Accordingly, the Poisson distribution is sometimes called the "law of small numbers" because it is the probability distribution of the number of occurrences of an event that happens rarely but has very many opportunities to happen. The Law of Small Numbers is a book by Ladislaus Bortkiewicz about the Poisson distribution, published in 1898. 法律一词有时被用作概率分布的同义词，法律的趋同意味着分配的趋同。因此，泊松分布有时被称为“小数定律” ，因为它是一个事件发生次数的概率分布，这个事件很少发生，但却有很多机会发生。小数定律》是拉迪斯劳斯·博特基威茨的一本关于泊松分布的书，出版于1898年。 --[[用户:fairywang|fairywang]]([[用户讨论:fairywang|讨论]]) 【审校】“泊松分布”改为“泊松分布” ===''' Poisson point process 泊松点过程'''=== {{Main|Poisson point process}} The Poisson distribution arises as the number of points of a [[Poisson point process]] located in some finite region. More specifically, if ''D'' is some region space, for example Euclidean space '''R'''\lt sup\gt ''d''\lt /sup\gt , for which |''D''|, the area, volume or, more generally, the Lebesgue measure of the region is finite, and if {{nowrap|''N''(''D'')}} denotes the number of points in ''D'', then The Poisson distribution arises as the number of points of a Poisson point process located in some finite region. More specifically, if D is some region space, for example Euclidean space R\lt sup\gt d\lt /sup\gt , for which |D|, the area, volume or, more generally, the Lebesgue measure of the region is finite, and if denotes the number of points in D, then 泊松分布是位于某个有限区域的泊松过程的点数。更具体地说，如果 d 是某个区域空间，例如欧几里德空间 r \lt sup \gt d \lt /sup \gt ，对于这个区域 | d | ，区域的面积、体积或者更一般地说，区域的勒贝格测度是有限的，如果表示 d 中的点数，那么 --[[用户:fairywang|fairywang]]([[用户讨论:fairywang|讨论]]) 【审校】“泊松分布”改为“泊松分布” : \lt math\gt P(N(D)=k)=\frac{(\lambda|D|)^k e^{-\lambda|D|}}{k!} . }[/math]

[math]\displaystyle{  P(N(D)=k)=\frac{(\lambda|D|)^k e^{-\lambda|D|}}{k!} . }[/math]

< math > p (n (d) = k) = frac {(lambda | d |) ^ k e ^ {-lambda | d | }{ k! }. math

Poisson regression and negative binomial regression 泊松回归与负二项回归

Poisson regression and negative binomial regression are useful for analyses where the dependent (response) variable is the count (0, 1, 2, ...) of the number of events or occurrences in an interval.

Poisson regression and negative binomial regression 泊松回归与负二项回归分析是有用的，其中依赖(响应)变量是计数(0,1,2，...)的在一个区间内事件发生的数量。

Other applications in science 科学上的其他应用

In a Poisson process, the number of observed occurrences fluctuates about its mean λ with a standard deviation [math]\displaystyle{ \sigma_k =\sqrt{\lambda} }[/math]. These fluctuations are denoted as Poisson noise or (particularly in electronics) as shot noise.

In a Poisson process, the number of observed occurrences fluctuates about its mean λ with a standard deviation [math]\displaystyle{ \sigma_k =\sqrt{\lambda} }[/math]. These fluctuations are denoted as Poisson noise or (particularly in electronics) as shot noise.

在泊松过程中，观察到的事件数目在其平均值上下波动，波动标准差为1/2。这些波动被称为泊松噪声或(特别是在电子学中)散粒噪声。

The correlation of the mean and standard deviation in counting independent discrete occurrences is useful scientifically. By monitoring how the fluctuations vary with the mean signal, one can estimate the contribution of a single occurrence, even if that contribution is too small to be detected directly. For example, the charge e on an electron can be estimated by correlating the magnitude of an electric current with its shot noise. If N electrons pass a point in a given time t on the average, the mean current is [math]\displaystyle{ I=eN/t }[/math]; since the current fluctuations should be of the order [math]\displaystyle{ \sigma_I=e\sqrt{N}/t }[/math] (i.e., the standard deviation of the Poisson process), the charge [math]\displaystyle{ e }[/math] can be estimated from the ratio [math]\displaystyle{ t\sigma_I^2/I }[/math].^{[citation needed]}

The correlation of the mean and standard deviation in counting independent discrete occurrences is useful scientifically. By monitoring how the fluctuations vary with the mean signal, one can estimate the contribution of a single occurrence, even if that contribution is too small to be detected directly. For example, the charge e on an electron can be estimated by correlating the magnitude of an electric current with its shot noise. If N electrons pass a point in a given time t on the average, the mean current is [math]\displaystyle{ I=eN/t }[/math]; since the current fluctuations should be of the order [math]\displaystyle{ \sigma_I=e\sqrt{N}/t }[/math] (i.e., the standard deviation of the Poisson process), the charge [math]\displaystyle{ e }[/math] can be estimated from the ratio [math]\displaystyle{ t\sigma_I^2/I }[/math].

在计算独立的离散事件时，平均数和标准差的相关性是有科学价值的。通过监测波动是如何随着平均信号而变化的，我们可以估计单一事件的贡献，即使这个贡献太小而不能直接检测到。例如，电子的电荷 e 可以通过将电流的大小与散粒噪声相关联来估计。如果 n 个电子在给定时间 t 平均通过一个点，那么平均电流为 < math > i = eN/t </math > ; 因为当前的波动应该是 < math > sigma i = e sqrt { n }/t </math > (即 Poisson 过程的标准差) ，所以电荷 < math > e </math > 可以通过数学比率 < t sigma _ i ^ 2/I </math > 来估计。

An everyday example is the graininess that appears as photographs are enlarged; the graininess is due to Poisson fluctuations in the number of reduced silver grains, not to the individual grains themselves. By correlating the graininess with the degree of enlargement, one can estimate the contribution of an individual grain (which is otherwise too small to be seen unaided).^{[citation needed]} Many other molecular applications of Poisson noise have been developed, e.g., estimating the number density of receptor molecules in a cell membrane.

An everyday example is the graininess that appears as photographs are enlarged; the graininess is due to Poisson fluctuations in the number of reduced silver grains, not to the individual grains themselves. By correlating the graininess with the degree of enlargement, one can estimate the contribution of an individual grain (which is otherwise too small to be seen unaided). Many other molecular applications of Poisson noise have been developed, e.g., estimating the number density of receptor molecules in a cell membrane.

一个日常的例子是放大照片时出现的颗粒状; 颗粒状是由于减少的银粒数量的泊松波动，而不是单个颗粒本身。通过将颗粒度与放大程度相关联，我们可以估算出单个颗粒的贡献(否则颗粒太小，无法单独看到)。泊松噪声的许多其他分子应用已经发展起来，例如，估计细胞膜上受体分子的数量密度。

[math]\displaystyle{ \lt math\gt 《数学》 \Pr(N_t=k) = f(k;\lambda t) = \frac{(\lambda t)^k e^{-\lambda t}}{k!}. }[/math]

   \Pr(N_t=k) = f(k;\lambda t) = \frac{(\lambda t)^k e^{-\lambda t}}{k!}.</math>

Pr (n _ t = k) = f (k; lambda t) = frac {((lambda t) ^ k e ^ {-lambda t }}{ k！} . </math >

In Causal Set theory the discrete elements of spacetime follow a Poisson distribution in the volume.

在 因果集合论Causal Set theory中，时空的离散元素在集合中遵循一个泊松分布。

 --fairywang(讨论)  【审校】“泊松分布”改为“泊松分布”

计算方法

泊松分布为专用软件库提出了两个不同的任务: 计算分布[math]\displaystyle{ P(k;\lambda) }[/math]，并根据分布绘制随机数。

计算泊松分布

计算[math]\displaystyle{ P(k;\lambda) }[/math]对于给定的[math]\displaystyle{ k }[/math]和[math]\displaystyle{ \lambda }[/math]是一项琐碎的任务，可以通过使用[math]\displaystyle{ P(k;\lambda) }[/math]的标准定义来完成，包括指数函数、幂函数和阶乘函数。然而，传统上对泊松分布的定义包含了两个容易在计算机上溢出的术语: λ^k!和 k。分数λ^k 到k!也可能产生舍入误差，与e^−λ相比，舍入误差非常大，因此给出错误的结果。因此，对于数值稳定性来说，泊松概率质量函数应该被评估为

[math]\displaystyle{ \!f(k; \lambda)= \exp \left[ k\ln \lambda - \lambda - \ln \Gamma (k+1) \right], }[/math]

这在数学上是等价的，但在数值上是稳定的。函数的自然对数可以使用 c 标准库(C99版本)中的lgamma函数或 R，MATLAB 或 SciPy 中的 gammaln函数，或 Fortran 2008及更高版本中的log_gamma函数来获得。

一些计算语言提供了 内置函数来计算泊松分布

R语言：function dpois(x, lambda)；

Microsoft Excel：function POISSON( x, mean, cumulative),带有一个标志来指定累积分布；

Mathematica：单变量泊松分布为PoissonDistribution[ λ ],^[8] ，二元泊松分布为MultivariatePoissonDistribution[θ_₁₂,{ θ_₁ - θ_₁₂,θ_₂ - θ_₁₂}]。^[9]

从泊松分布中抽取随机量

更简单的任务是用给定的[math]\displaystyle{ \lambda }[/math]从泊松分布中提取随机整数。

提供解决方案的有:

R语言: 函数rpois(n, lambda);

GSL函数库: 函数 gsl_ran_poisson

<br》

生成泊松分布随机变量

给出了一个产生随机泊松分布数(伪随机数抽样)的简单算法:

算法：泊松随机数 Knuth
  初始化：
    设 L ← e^−λ, k ← 0 且 p ← 1.
  执行：
    k ← k + 1.
    在[0,1]中生成均匀随机数 u 并且设 p ← p × u。
  同时 p > L.
  返回 k − 1.

返回值k的复杂度是线性的，平均为λ。还有许多其他的算法可以改进这一点。一些是在 Ahrens & Dieter，见下面。

对于λ较大的值，L = e^−λ的值可能非常小，以至于很难表示。这可以通过改变算法来解决，该算法使用附加参数 STEP，使得e^−STEP不会下溢:

算法：泊松随机数 Junhao（基于 Knuth） :
  初始化：
    设Let λLeft ← λ, k ← 0 且 p ← 1.
  执行：
    k ← k + 1.
    在(0,1)中生成均匀随机数 u 并且设p ← p × u
    而 p < 1 and λLeft > 0:
    如果 λLeft > STEP:
      p ← p × e^STEP
      λLeft ← λLeft − STEP
    或者:
      p ← p × e^λLeft
      λLeft ← 0 同时 p > 1。
  返回 k − 1.

STEP 的选择取决于溢出阈值。对于双精度浮点格式，阈值接近e⁷⁰⁰，因此500应该是一个安全的 STEP。

其他λ的大数值的求解包括抑制取样和使用高斯近似 Gaussian approximation。

逆变换采样对于λ小数值的样本是简单有效的，并且每个样本只需要一个均匀一致的随机数u。依次检查累积概率，直到其超过u。

算法：基于顺序检索反演的泊松发生器算法 Algorithm Poisson generator:
  初始化:
    设 x ← 0, p ← e^−λ, s ← p.
    在[0,1]中生成均匀随机数 u，同时 u > s
  执行：
    x ← x + 1.
    p ← p × λ / x.
    s ← s + p.
  返回 x

历史

这种分布最早由西蒙·丹尼斯·泊松 Siméon Denis Poisson（1781-1840）提出，并与他的概率论一起发表在他的著作Recherches sur la probabilité des jugements en matière criminelle et en matière Civile (1837) 中。这项工作通过关注某些随机变量N，其中包括在给定时间间隔内发生的离散事件（有时称为“事件”或“到达事件”）的数量来推断某一国家的错误定罪数量。这个结果早在1711年就已由亚伯拉罕·德·莫弗 Abraham de Moivre给出了。这使它成为斯蒂格勒定律 Stigler's law的一个例子，也使一些作者提出，泊松分布应该以de Moivre的名字命名。

1860年，Simon Newcomb 将泊松分布与天文台一个空间单位中发现的恒星数量进行了比较。

这种分布的进一步实际应用是在1898年，当时拉迪斯劳斯·博特基威茨被赋予任务调查普鲁士军队中被马踢意外杀死的士兵人数; 这个实验将泊松分布引入可靠性技术领域。

参考文献

引用

↑ Proof wiki: expectation and Proof wiki: variance
↑ [ http://www.proofwiki.org/wiki/expectation_of_poisson_distribution 证明 wiki: 期望]和[ http://www.proofwiki.org/wiki/variance_of_poisson_distribution 证明 wiki: variance ]
↑ "1.7.7 – Relationship between the Multinomial and Poisson | STAT 504".
↑ Free Random Variables by D. Voiculescu, K. Dykema, A. Nica, CRM Monograph Series, American Mathematical Society, Providence RI, 1992
↑ James A. Mingo, Roland Speicher: Free Probability and Random Matrices. Fields Institute Monographs, Vol. 35, Springer, New York, 2017.
↑ Lectures on the Combinatorics of Free Probability by A. Nica and R. Speicher, pp. 203–204, Cambridge Univ. Press 2006
↑ Paszek, Ewa. "Maximum Likelihood Estimation – Examples".
↑ "Wolfram Language: PoissonDistribution reference page". wolfram.com. Retrieved 2016-04-08.
↑ "Wolfram Language: MultivariatePoissonDistribution reference page". wolfram.com. Retrieved 2016-04-08.

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资源

Ahrens, Joachim H.; Dieter, Ulrich (1974), "Computer Methods for Sampling from Gamma, Beta, Poisson and Binomial Distributions", Computing, 12 (3): 223–246, doi:10.1007/BF02293108
Ahrens, Joachim H.; Dieter, Ulrich (1982), "Computer Generation of Poisson Deviates", ACM Transactions on Mathematical Software, 8 (2): 163–179, doi:10.1145/355993.355997
Evans, Ronald J.; Boersma, J.; Blachman, N. M.; Jagers, A. A. (1988), "The Entropy of a Poisson Distribution: Problem 87-6", SIAM Review, 30 (2): 314–317, doi:10.1137/1030059

[1] Proof wiki: expectation and Proof wiki: variance

[2] [ http://www.proofwiki.org/wiki/expectation_of_poisson_distribution 证明 wiki: 期望]和[ http://www.proofwiki.org/wiki/variance_of_poisson_distribution 证明 wiki: variance ]

[3] "1.7.7 – Relationship between the Multinomial and Poisson | STAT 504".

[4] Free Random Variables by D. Voiculescu, K. Dykema, A. Nica, CRM Monograph Series, American Mathematical Society, Providence RI, 1992

[5] James A. Mingo, Roland Speicher: Free Probability and Random Matrices. Fields Institute Monographs, Vol. 35, Springer, New York, 2017.

[6] Lectures on the Combinatorics of Free Probability by A. Nica and R. Speicher, pp. 203–204, Cambridge Univ. Press 2006

[7] Paszek, Ewa. "Maximum Likelihood Estimation – Examples".

[WLPoissonRefPage-8] "Wolfram Language: PoissonDistribution reference page". wolfram.com. Retrieved 2016-04-08.

[WLMvPoissonRefPage-9] "Wolfram Language: MultivariatePoissonDistribution reference page". wolfram.com. Retrieved 2016-04-08.

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@@ 第1,941行： / 第1,941行： @@
    --[[用户:fairywang|fairywang]]([[用户讨论:fairywang|讨论]])  【审校】“泊松分布”改为“泊松分布”
-==Computational methods计算方法==
+==计算方法==
-The Poisson distribution poses two different tasks for dedicated software libraries: ''Evaluating'' the distribution <math>P(k;\lambda)</math>, and ''drawing random numbers'' according to that distribution.
-The Poisson distribution poses two different tasks for dedicated software libraries: Evaluating the distribution <math>P(k;\lambda)</math>, and drawing random numbers according to that distribution.
-泊松分布为专用软件库提出了两个不同的任务: 评估分布 < math > p (k; lambda) </math > ，并根据分布绘制随机数。
+泊松分布为专用软件库提出了两个不同的任务: 计算分布<math>P(k;\lambda)</math>，并根据分布绘制随机数。
 ===计算泊松分布===
 计算<math>P(k;\lambda)</math>对于给定的<math>k</math>和<math>\lambda</math>是一项琐碎的任务，可以通过使用<math>P(k;\lambda)</math>的标准定义来完成，包括指数函数、幂函数和阶乘函数。然而，传统上对泊松分布的定义包含了两个容易在计算机上溢出的术语: λ<sup>''k''</sup>!和 ''k''。分数λ<sup>''k''</sup> 到''k''!也可能产生舍入误差，与''e''<sup>−λ</sup>相比，舍入误差非常大，因此给出错误的结果。因此，对于数值稳定性来说，泊松概率质量函数应该被评估为

“泊松分布”的版本间的差异

2021年11月14日 (日) 17:24的版本

Definitions定义

Probability mass function概率分布函数

Example举例

Assumptions and validity假设与有效条件

Probability of events for a Poisson distribution {泊松分布 Poisson distribution的事件概率

Examples of probability for Poisson distributions {泊松分布 Poisson distribution概率的示例

Once in an interval events: The special case of λ = 1 and k = 0 事件唯一发生：λ = 1 与 k = 0的特殊情形

Examples that violate the Poisson assumptions 违反泊松假设的例子

Properties 性能

描述统计学Descriptive statistics

Median 中值

Higher moments 高阶矩

Sums of Poisson-distributed random variables 泊松分布随机变量和

Other properties 其他特性

Poisson races 泊松族群

' 相关分布'Related distributions

Genera通常l

Poisson Approximation 泊松近似

二元泊松分布Bivariate Poisson distribution

自由泊松分布Free Poisson distribution

Some transforms of this law这一定律的一些变换

Statistical Inference 统计学推论

Parameter estimation参数估计

Confidence interval 置信区间Confidence interval

Bayesian inference 贝叶斯推理

Simultaneous estimation of multiple Poisson means 多重泊松均值的同步估计

Occurrence and applications 发生与应用

Law of rare events稀有事件定律

Poisson regression and negative binomial regression 泊松回归与负二项回归

Other applications in science 科学上的其他应用

计算方法

计算泊松分布

从泊松分布中抽取随机量

生成泊松分布随机变量

历史

参考文献

引用

资源

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