Abstract
A recurrence formula for absolute central moments of Poisson distribution is suggested.
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Let X be a Poisson random variable with mean m. In this paper, we study absolute central moments \(\mathbf{E} |X-a|^r\) about a for naturals r. Explicit representations for such moments may be useful in situations where we want to test whether observations in a large sample are independent Poisson with given means, which is the case, for instance, for some image reconstruction techniques in emission tomography (e.g., see [1, 4]).
An explicit representation for the mean deviation was obtained independently in [3, 7]:
where \(\lfloor \cdot \rfloor\) denotes the floor function.
Kendall ([6], relations (5.21) and (5.22) on p. 121) has showed that for all integers \(r\ge 2\),
Denote by \(_1\! F_1\) the confluent hypergeometric function of the first kind
where \(\prod _{j=0}^{-1} =1\). Katti [5] has derived the following representation for absolute central moments of X about a for all odd \(r\ge 1\):
where
\(G^{(r)}(\beta ,t)\) is its r-th partial derivative with respect to t, which, for \(t=0\), can be computed by the recurrence formula
for \(s= 1,2,\ldots\), where
The main goal of this paper is to suggest a simpler recurrence formula for absolute central moments of X about a.
Define the sign function
and put
where \(0^0=1\) by definition, f is a real-valued function. Here, F(b) is the cumulative distribution function of X, and C(r, a) is the r-th central moment about a. The above definition of the sign function is not common for \(y=0\), but is chosen here for the sake of convenience, to provide the equality
We have
For all integers \(r\ge 1\) , reals \(b\ge 0\) and a , and functions f such that
\(\mathbf{E}X^r |f(X)|<\infty\) , the following recurrence relations are valid:
where \(0^0=1\) by definition,
and all the expectations B are finite.
FormalPara Remark 1The same approach can be used to obtain similar relations for binomial and hypergeometric distributions.
FormalPara Corollary 1Notice that the cumulative distribution function F can be calculated, e.g., by the built-in function ppois() in R or by the function scipy.stats.poisson.cdf() in Python.
In order to validate the formulas of the corollary, we ran the following simple simulation. For each considered value of m, we computed \(\mathbf{E} |X-m|^r\) for \(r=3\) or 5: by the formulas of Corollary 1; by direct computation
where the \(\mathrm{lfactorial}\) function is the natural logarithm of factorial; and by the law of large numbers (l.l.n.). In the last case, we calculated, for each value of r and m, 10,000 independent draws of \(\frac{1}{10,000} \sum _{j=1}^{10,000} |X_j-m|^r,\) where \(X_1,X_2,\ldots\) are independent Poisson random variables with mean m; and reported the empirical mean and standard error among the draws. The computations were done in R v. 3.6.3. Thus, 64-bit reals were used, which corresponds to the precision of 15–17 decimal digits. The results are shown in the following table, where the results of exact computations are presented by 16 decimal digits, while the results for the l.l.n. are presented as empirical mean (7 decimal digits) ± standard error (4 decimal digits):
\(m=0.1\) | \(m=1.2\) | \(m=12.3\) | \(m=123.4\) | |
---|---|---|---|---|
\(r=3\), Corollary 1 | 0.1018096748360720 | 2.246710125237284 | 69.30382763917270 | 2188.950302642536 |
\(r=3\), (10) | 0.1018096748360720 | 2.246710125237284 | 69.30382763917289 | 2188.950302642802 |
\(r=3\), l.l.n. | 0.1017273 ± 0.00005931 | 2.245930 ± 0.0007664 | 69.29764 ± 0.01628 | 2189.144 ± 0.4905 |
\(r=5\), Corollary 1 | 0.2000180967483608 | 17.09916647992549 | 3616.415042490471 | 1087028.898973938 |
\(r=5\), (10) | 0.2000180967483608 | 17.09916647992548 | 3616.415042490486 | 1087028.898974066 |
\(r=5\), l.l.n. | 0.1996778 ± 0.0003536 | 17.07592 ± 0.01850 | 3614.712 ± 2.189 | 1,087,175 ± 531.8 |
The results of the computations justify the correctness of the formulas of Corollary 1.
First, let us prove (7). By Proposition 1 in Borisov and Ruzankin [2, p. 1660], we have the equivalences
where the \(\Leftrightarrow\) sign means “if and only if”, \(\Delta ^r\) means applying the \(\Delta\) operator r times. Hence, all the expectations B in (7) are finite. For \(r\ge 1\), we have
Analogously, (11) implies (6).
which proves (7). \(\square\)
Let us now prove (7). By (11), for \(r\ge 1\), we have
which proves (8). Notice that \(\mathrm{sign} (j+1-b) \ne \mathrm{sign} (j-b)\) for \(j=\lfloor b \rfloor\) only. Hence, (12) equals
which proves (7).
The theorem is proved.
References
Ben Bouallègue F, Crouzet JF, Mariano-Goulart D (2013) A heuristic statistical stopping rule for iterative reconstruction in emission tomography. Ann Nucl Med 27:84–95
Borisov IS, Ruzankin PS (2002) Poisson approximation for expectations of unbounded functions of independent random variables. Ann Probab 30(4):1657–1680
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Hebert TJ (1990) Statistical stopping criteria for iterative maximum likelihood reconstruction of emission images. Phys Med Biol 35:1221–1232
Katti SK (1960) Moments of the absolute difference and absolute deviation of discrete distributions. Ann Math Stat 31(1):78–85
Kendall MG (1943) The advanced theory of statistics, vol 1. Griffin, London
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Acknowledgements
This work was supported by Russian Foundation for Basic Research (Grants 17-52-14004 and 18-01-00074).
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Ruzankin, P.S. On Absolute Central Moments of Poisson Distribution. J Stat Theory Pract 14, 56 (2020). https://doi.org/10.1007/s42519-020-00121-8
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DOI: https://doi.org/10.1007/s42519-020-00121-8