Mixed Poisson distribution

mixed Poisson distribution
Notation
Parameters
Support
PMF
Mean
Variance
Skewness
MGF	, with the MGF of π
CF
PGF

A mixed Poisson distribution is a univariate discrete probability distribution in stochastics. It results from assuming that the conditional distribution of a random variable, given the value of the rate parameter, is a Poisson distribution, and that the rate parameter itself is considered as a random variable. Hence it is a special case of a compound probability distribution. Mixed Poisson distributions can be found in actuarial mathematics as a general approach for the distribution of the number of claims and is also examined as an epidemiological model.^[1] It should not be confused with compound Poisson distribution or compound Poisson process.^[2]

Definition

A random variable X satisfies the mixed Poisson distribution with density $π$ (λ) if it has the probability distribution^[3]

\operatorname {P} (X=k)=\int _{0}^{\infty }{\frac {\lambda ^{k}}{k!}}e^{-\lambda }\,\,\pi (\lambda )\,\mathrm {d} \lambda .

If we denote the probabilities of the Poisson distribution by q_λ(k), then

\operatorname {P} (X=k)=\int _{0}^{\infty }q_{\lambda }(k)\,\,\pi (\lambda )\,\mathrm {d} \lambda .

Properties

The variance is always bigger than the expected value. This property is called overdispersion. This is in contrast to the Poisson distribution where mean and variance are the same.
In practice, almost only densities of gamma distributions, logarithmic normal distributions and inverse Gaussian distributions are used as densities $π$ (λ). If we choose the density of the gamma distribution, we get the negative binomial distribution, which explains why this is also called the Poisson gamma distribution.

In the following let $\mu _{\pi }=\int \limits _{0}^{\infty }\lambda \,\,\pi (\lambda )\,d\lambda \,$ be the expected value of the density $\pi (\lambda )\,$ and $\sigma _{\pi }^{2}=\int \limits _{0}^{\infty }(\lambda -\mu _{\pi })^{2}\,\,\pi (\lambda )\,d\lambda \,$ be the variance of the density.

Expected value

The expected value of the mixed Poisson distribution is

\operatorname {E} (X)=\mu _{\pi }.

Variance

For the variance one gets^[3]

\operatorname {Var} (X)=\mu _{\pi }+\sigma _{\pi }^{2}.

Skewness

The skewness can be represented as

\operatorname {v} (X)={\Bigl (}\mu _{\pi }+\sigma _{\pi }^{2}{\Bigr )}^{-3/2}\,{\Biggl [}\int _{0}^{\infty }(\lambda -\mu _{\pi })^{3}\,\pi (\lambda )\,d{\lambda }+\mu _{\pi }{\Biggr ]}.

Characteristic function

The characteristic function has the form

\varphi _{X}(s)=M_{\pi }(e^{is}-1).\,

Where $M_{\pi }$ is the moment generating function of the density.

Probability generating function

For the probability generating function, one obtains^[3]

m_{X}(s)=M_{\pi }(s-1).\,

Moment-generating function

The moment-generating function of the mixed Poisson distribution is

M_{X}(s)=M_{\pi }(e^{s}-1).\,

Examples

Theorem — Compounding a Poisson distribution with rate parameter distributed according to a gamma distribution yields a negative binomial distribution.^[3]

Proof

Let $\pi (\lambda )={\frac {({\frac {p}{1-p}})^{r}}{\Gamma (r)}}\lambda ^{r-1}e^{-{\frac {p}{1-p}}\lambda }$ be a density of a $\operatorname {\Gamma } \left(r,{\frac {p}{1-p}}\right)$ distributed random variable.

${\begin{aligned}\operatorname {P} (X=k)&={\frac {1}{k!}}\int _{0}^{\infty }\lambda ^{k}e^{-\lambda }{\frac {({\frac {p}{1-p}})^{r}}{\Gamma (r)}}\lambda ^{r-1}e^{-{\frac {p}{1-p}}\lambda }\,\mathrm {d} \lambda \\&={\frac {p^{r}(1-p)^{-r}}{\Gamma (r)k!}}\int _{0}^{\infty }\lambda ^{k+r-1}e^{-\lambda {\frac {1}{1-p}}}\,\mathrm {d} \lambda \\&={\frac {p^{r}(1-p)^{-r}}{\Gamma (r)k!}}(1-p)^{k+r}\underbrace {\int _{0}^{\infty }\lambda ^{k+r-1}e^{-\lambda }\,\mathrm {d} \lambda } _{=\Gamma (r+k)}\\&={\frac {\Gamma (r+k)}{\Gamma (r)k!}}(1-p)^{k}p^{r}\end{aligned}}$

Therefore we get $X\sim \operatorname {NegB} (r,p).$

Theorem — Compounding a Poisson distribution with rate parameter distributed according to a exponential distribution yields a geometric distribution.

Proof

Let $\pi (\lambda )={\frac {1}{\beta }}e^{-{\frac {\lambda }{\beta }}}$ be a density of a $\mathrm {Exp} \left({\frac {1}{\beta }}\right)$ distributed random variable. Using integration by parts n times yields: ${\begin{aligned}\operatorname {P} (X=k)&={\frac {1}{k!}}\int \limits _{0}^{\infty }\lambda ^{k}e^{-\lambda }{\frac {1}{\beta }}e^{-{\frac {\lambda }{\beta }}}\,\mathrm {d} \lambda \\&={\frac {1}{k!\beta }}\int \limits _{0}^{\infty }\lambda ^{k}e^{-\lambda \left({\frac {1+\beta }{\beta }}\right)}\,\mathrm {d} \lambda \\&={\frac {1}{k!\beta }}\cdot k!\left({\frac {\beta }{1+\beta }}\right)^{k}\int \limits _{0}^{\infty }e^{-\lambda \left({\frac {1+\beta }{\beta }}\right)}\,\mathrm {d} \lambda \\&=\left({\frac {\beta }{1+\beta }}\right)^{k}\left({\frac {1}{1+\beta }}\right)\end{aligned}}$ Therefore we get $X\sim \operatorname {Geo\left({\frac {1}{1+\beta }}\right)} .$

Table of mixed Poisson distributions

mixing distribution	mixed Poisson distribution^[4]
gamma	negative binomial
exponential	geometric
inverse Gaussian	Sichel
Poisson	Neyman
generalized inverse Gaussian	Poisson-generalized inverse Gaussian
generalized gamma	Poisson-generalized gamma
generalized Pareto	Poisson-generalized Pareto
inverse-gamma	Poisson-inverse gamma
log-normal	Poisson-log-normal
Lomax	Poisson–Lomax
Pareto	Poisson–Pareto
Pearson’s family of distributions	Poisson–Pearson family
truncated normal	Poisson-truncated normal
uniform	Poisson-uniform
shifted gamma	Delaporte
beta with specific parameter values	Yule

Literature

Jan Grandell: Mixed Poisson Processes. Chapman & Hall, London 1997, ISBN 0-412-78700-8 .
Tom Britton: Stochastic Epidemic Models with Inference. Springer, 2019, doi:10.1007/978-3-030-30900-8

References

^ Willmot, Gordon E.; Lin, X. Sheldon (2001), "Mixed Poisson distributions", Lundberg Approximations for Compound Distributions with Insurance Applications, Lecture Notes in Statistics, vol. 156, New York, NY: Springer New York, pp. 37–49, doi:10.1007/978-1-4613-0111-0_3, ISBN 978-0-387-95135-5, retrieved 2022-07-08
^ Willmot, Gord (1986). "Mixed Compound Poisson Distributions". ASTIN Bulletin. 16 (S1): S59–S79. doi:10.1017/S051503610001165X. ISSN 0515-0361.
^ ^a ^b ^c ^d Willmot, Gord (2014-08-29). "Mixed Compound Poisson Distributions". Astin Bulletin. 16: 5–7. doi:10.1017/S051503610001165X. S2CID 17737506.
^ Karlis, Dimitris; Xekalaki, Evdokia (2005). "Mixed Poisson Distributions". International Statistical Review. 73 (1): 35–58. doi:10.1111/j.1751-5823.2005.tb00250.x. ISSN 0306-7734. JSTOR 25472639. S2CID 53637483.

[1] Willmot, Gordon E.; Lin, X. Sheldon (2001), "Mixed Poisson distributions", Lundberg Approximations for Compound Distributions with Insurance Applications, Lecture Notes in Statistics, vol. 156, New York, NY: Springer New York, pp. 37–49, doi:10.1007/978-1-4613-0111-0_3, ISBN 978-0-387-95135-5, retrieved 2022-07-08

[2] Willmot, Gord (1986). "Mixed Compound Poisson Distributions". ASTIN Bulletin. 16 (S1): S59–S79. doi:10.1017/S051503610001165X. ISSN 0515-0361.

[Willmot-3] Willmot, Gord (2014-08-29). "Mixed Compound Poisson Distributions". Astin Bulletin. 16: 5–7. doi:10.1017/S051503610001165X. S2CID 17737506.

[4] Karlis, Dimitris; Xekalaki, Evdokia (2005). "Mixed Poisson Distributions". International Statistical Review. 73 (1): 35–58. doi:10.1111/j.1751-5823.2005.tb00250.x. ISSN 0306-7734. JSTOR 25472639. S2CID 53637483.

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Notation	$\operatorname {Pois} (\lambda )\,{\underset {\lambda }{\wedge }}\,\pi (\lambda )$
Parameters	$\lambda \in (0,\infty )$
Support	$k\in \mathbb {N} _{0}$
PMF	$\int \limits _{0}^{\infty }{\frac {\lambda ^{k}}{k!}}e^{-\lambda }\,\,\pi (\lambda )\,\mathrm {d} \lambda$
Mean	$\int \limits _{0}^{\infty }\lambda \,\,\pi (\lambda )\,d\lambda$
Variance	$\int \limits _{0}^{\infty }(\lambda +(\lambda -\mu _{\pi })^{2})\,\,\pi (\lambda )\,d\lambda$
Skewness	${\Bigl (}\mu _{\pi }+\sigma _{\pi }^{2}{\Bigr )}^{-3/2}\,{\Biggl [}\int \limits _{0}^{\infty }[(\lambda -\mu _{\pi })^{3}+3(\lambda -\mu _{\pi })^{2}]\,\pi (\lambda )\,d{\lambda }+\mu _{\pi }{\Biggr ]}$
MGF	$M_{\pi }(e^{t}-1)$ , with $M_{\pi }$ the MGF of $π$
CF	$M_{\pi }(e^{it}-1)$
PGF	$M_{\pi }(z-1)$