A Generalized Multinomial Distribution from Dependent Categorical Random Variables

A Generalized Multinomial Distribution from Dependent Categorical Random Variables

For the full paper, which includes all proofs, download the pdf  here.

Generalized Multinomial Distribution

From the construction in Section 2, we derive a generalized multinomial distribution in which all categorical variables are identically distributed but no longer independent.


Theorem 2: Generalized Multinomial Distribution.  Let \epsilon_{1},\ldots,\epsilon_{N} be categorical random variables with categories 1,\ldots,K, constructed as in Section 2. Let X_{i} = \sum_{j=1}^{N}[\epsilon_{j} = i], i = 1,\ldots,K, where [\cdot] is the Iverson bracket. Denote \mathbf{X} = (X_{1},\ldots,X_{K}), with observed values \mathbf{x} = (x_{1},\ldots,x_{K}). Then

P(\mathbf{X} = \mathbf{x}) = \sum_{i=1}^{K}p_{i}\frac{(N-1)!}{(x_{i}-1)!\prod_{j \neq i}x_{j}!}\left(p_{i}^{+}\right)^{x_{i}-1}\prod_{j \neq i}\left(p_{j}^{-}\right)^{x_{j}}.


 

Properties

This section details some useful properties of the Generalized Multinomial Distribution and the dependent categorical random variables.

Marginal Distributions

Theorem 3: Univariate Marginal Distribution.  The univariate marginal distribution of the Generalized Multinomial Distribution is the Generalized Binomial Distribution. That is,

P(X_{i} = x_{i}) = q{N-1 \choose x_{i}}\left(p_{i}^{-}\right)^{x_{i}}\left(q^{-}\right)^{N-1-x_{i}} + p_{i}{N-1 \choose x_{i}-1}\left(p_{i}^{+}\right)^{x_{i}-1}\left(q^{+}\right)^{N-1-(x_{i}-1)},
where q = \sum_{j \neq i}p_{j}, q^{+} = q + \delta p_{i}, and q^{-} = q - \delta q.
The above theorem shows another way the generalized multinomial distribution is an extension of the generalized binomial distribution.

Theorem 4: Moment Generating Function.  The moment generating function of the generalized multinomial distribution with K categories is given by
M_{\mathbf{X}}(\mathbf{t}) = \sum_{i=1}^{K}p_{i}e^{t_{i}}\left(p_{i}^{+}e^{t_{i}} + \sum_{j \neq i}p_{j}^{-}e^{t_{j}}\right)^{n-1}

where \mathbf{X} = (X_{1},...,X_{K}) and \mathbf{t} = (t_{1},...,t_{K}).

Moments of the Generalized Multinomial Distribution

Using the moment generating function in the standard way, the mean vector \mu and the covariance matrix \Sigma may be derived.

Expected Value. The expected value of \mathbf{X} is given by \mu = n\mathbf{p} where \mathbf{p} = (p_{1},...,p_{K})

Covariance Matrix The entries of the covariance matrix are given by
\Sigma_{ij} = \left\{\begin{array}{lr}p_{i}(1-p_{i})(n + \delta(n-1) + \delta^{2}(n-1)(n-2)), & i = j \\p_{i}p_{j}(\delta(1-\delta)(n-2)(n-1)-n), & i \neq j\end{array}\right. Note that if \delta = 0, the generalized multinomial distribution reduces to the standard multinomial distribution and \Sigma becomes the familiar multinomial covariance matrix. The entries of the corresponding correlation matrix are given by
\rho(X_{i},X_{j}) = -\sqrt{\frac{p_{i}p_{j}}{(1-p_{i})(1-p_{j})}}\left(\frac{n-\delta(n-1)(n-2)}{n+\delta(n-1)+\delta^{2}(n-1)(n-2)}\right)

If \delta = 1, the variance of X_{i} tends to \infty with n. This is intuitive, as \delta = 1 implies perfect dependence of \epsilon_{2},...,\epsilon_{n} on the outcome of \epsilon_{1}. Thus, X_{i} will either be 0 or n, and this spread increases to \infty with n.