The COPULA Procedure (Experimental)

Normal Copula

Let $u_ j \sim U(0,1)$ for $j=1,\ldots ,m$, where $U(0,1)$ represents the uniform distribution on the $[0,1]$ interval. Let $\Sigma $ be the correlation matrix with $m(m-1)/2$ parameters satisfying the positive semidefiniteness constraint. The normal copula can be written as

\begin{equation*}  C_{\Sigma }(u_1, u_2,{\ldots } u_ m) = \bm {\Phi }_\Sigma \Bigl (\Phi ^{-1} (u_1),{\ldots } \Phi ^{-1} (u_ m)\Bigr ) \end{equation*}

where $\Phi $ is the distribution function of a standard normal random variable and $\bm {\Phi }_\Sigma $ is the $m$-variate standard normal distribution with mean vector $0$ and covariance matrix $\Sigma $. That is, the distribution $\bm {\Phi }_\Sigma $ is $N_ m(0,\Sigma )$.


For the normal copula, the input of the simulation is the correlation matrix $\Sigma $. The normal copula can be simulated by the following steps in which $\bm U= (U_1,\ldots ,U_ m)$ denotes one random draw from the copula:

  1. Generate a multivariate normal vector $\bm Z \sim N(0,\Sigma )$ where $\Sigma $ is an $m$-dimensional correlation matrix.

  2. Transform the vector $\bm Z$ into $\bm U= (\Phi (Z_1),\ldots ,\Phi (Z_ m))^ T$, where $\Phi $ is the distribution function of univariate standard normal.

The first step can be achieved by Cholesky decomposition of the correlation matrix $\Sigma =LL^ T$ where $L$ is a lower triangular matrix with positive elements on the diagonal. If $\bm {\tilde{Z}} \sim N(0,I)$, then $L\bm {\tilde{Z}} \sim N(0,\Sigma )$.


To fit a normal copula is to estimate the covariance matrix $\Sigma $ from an input sample data set. Given a random sample $\bm u_ i = (u_{i,1},\ldots ,u_{i,m})^\top $ where $i=1,\ldots ,n$, the log-likelihood function is

$\displaystyle  $
$\displaystyle \log L(\Sigma ;\bm u_1,\ldots , \bm u_ n) $
$\displaystyle  $
$\displaystyle =\sum _{t=1}^ n \log f_\Sigma (\Phi ^{-1}(u_{t,1}),\ldots ,\Phi ^{-1}(u_{t,m})) -\sum _{t=1}^ n \sum _{j=1}^ m \log \phi (\Phi ^{-1}(u_{t,j}))  $

Here $ f_\Sigma $ is the joint density of the multivariate normal with mean zero and variance $\Sigma $, and $\phi $ is the univariate density of the standard normal distribution. Note that the second term is not related to the parameters $\Sigma $ and, therefore, can be ignored during the optimization. The restriction that $\Sigma $ is a correlation matrix is very inconvenient, and it is common practice to circumvent this problem by first assuming that $\Sigma $ has the covariance form. Therefore, $\Sigma $ can be estimated by

\[  \widehat{\Sigma } = \frac{1}{n} \sum _{i=1}^{n} \bm {\zeta }_ i \bm {\zeta }_ i^ T  \]


\[  \bm {\zeta }_ i = \bigl (\Phi ^{-1}(u_{i,1}),\Phi ^{-1}(u_{i,2}),{\ldots },\Phi ^{-1}(u_{i,m})\bigr )^ T  \]

This estimate is consistent with the form of a covariance matrix but not necessarily with the form of a correlation matrix. The approximation to the original MLE problem can be obtained using the normalizing operator defined as follows:

$\displaystyle  \Delta (\Sigma )  $
$\displaystyle = \textrm{diag}(\sigma _{11}^{1/2},\ldots ,\sigma _{mm}^{1/2}) $
$\displaystyle \mathcal{P}(\Sigma ) $
$\displaystyle = (\Delta (\Sigma ))^{-1} \Sigma (\Delta (\Sigma ))^{-1}  $