Derivation of moment generating function for limiting distribution of sum of logbeta distributed variables A sum of logbeta distributed variables occurs in this question Distribution with a given moment generating function
Let, $X_j \sim Beta(j\sigma, 1-\sigma)$, $Y_j = -\log(X_j)$ and $S_n = \sum_{j=1}^n Y_j - \frac{1-\sigma}{\sigma}\log(n)$ then the moment generating function of $S_n$ approaches, for $n \to \infty$
$$E(e^{tS_n}) \to \frac{\Gamma(1-t/\sigma)}{\sigma^t\Gamma(1-t)}$$
How is this derived?
 A: The expectation of $E(e^{tS_n})$ is similar to $E(Z_{n,t})$ where $Z_{n,t}$ is a product
$$Z_{n,t} = e^{tS_n} = e^{-t\sum_{j=1}^n \log X_j -t \frac{1-\sigma}{\sigma} \log(n)}= \left( n^{(1-\sigma)/\sigma} \prod_{j=1}^n X_j \right)^{-t}$$
And the expectation of a product of independent variables is the product of the expectation of the individual variables
$$E(Z_{n,t}) = n^{-t(1-\sigma)/\sigma}  \prod_{j=1}^n E( X_j^{-t}) $$
The expectation $E(X_j^{-t})$ for a beta distribution is
$$E(X_j^{-t}) = \frac{1}{B(\alpha,\beta)} \int_0^1 x^{-t} x^{\alpha-1}(1-x)^{\beta-1} dx = \frac{B(\alpha-t,\beta)}{B(\alpha,\beta)}$$
We get to
$$E(e^{tS_n}) = n^{-t(1-\sigma)/\sigma} \prod_{j=1}^n  \frac{B(j\sigma-t,1-\sigma)}{B(j\sigma,1-\sigma)} $$
We can rewrite the beta function in terms of gamma functions $B(x,y) = \Gamma(x)\Gamma(y)/\Gamma(x+y)$
$$\begin{array}{}
E(e^{tS_n}) & = & n^{-t(1-\sigma)/\sigma} \prod_{j=1}^n  \frac{\Gamma(j\sigma-t)}{\Gamma(j\sigma-t+1-\sigma)} \frac{\Gamma(j\sigma+1-\sigma)}{\Gamma(j\sigma)} \\ &=& n^{-t(1-\sigma)/\sigma} \prod_{j=1}^n  \frac{\Gamma(j\sigma-t+1)}{\Gamma((j-1)\sigma-t+1)} \cdot \frac{\Gamma((j-1)\sigma+1)}{\Gamma(j\sigma+1)} \cdot  \frac{j\sigma}{j\sigma-t}
\end{array}$$
in the second line we rewrote the gamma function such that we get terms $\Gamma((j-1)\sigma+1)$ and $\Gamma(j\sigma+1)$ where the difference is only in $j$ versus $j-1$. This makes that many terms cancel because in the sum they appear both once in the numerator and once in the denominator.
$$\begin{array}{}
E(e^{tS_n}) &=& n^{-t(1-\sigma)/\sigma}   \frac{1}{\Gamma(1-t)}  \cdot \frac{\Gamma(n\sigma + 1 -t)}{\Gamma(n\sigma +1)} \cdot  \prod_{j=1}^n  \frac{j\sigma}{j\sigma-t} \\
\end{array}$$
using $\Gamma(1+z) = \prod_{j=1}^{\infty} \frac{(1+1/j)^z}{1+z/j}$
$$\begin{array}{}
E(e^{tS_n})  &=& n^{-t(1-\sigma)/\sigma}   \frac{1}{\Gamma(1-t)}  \cdot  \frac{\Gamma(n\sigma + 1 -t)}{\Gamma(n\sigma +1)} \cdot \prod_{j=1}^n  \frac{1}{1-\frac{t/\sigma}{j}} \\
 &=& n^{-t(1-\sigma)/\sigma}   \frac{\Gamma(1-t/\sigma)}{\Gamma(1-t)} \cdot \frac{\Gamma(n\sigma + 1 -t)}{\Gamma(n\sigma +1)} \cdot  \prod_{j=1}^n  \frac{1}{1-\frac{t/\sigma}{j}} \prod_{j=1}^\infty  \frac{1-\frac{t/\sigma}{j}}{(1+1/j)^{-t/\sigma}} \\
 &=& n^{-t(1-\sigma)/\sigma}   \frac{\Gamma(1-t/\sigma)}{\Gamma(1-t)} \cdot \frac{\Gamma(n\sigma + 1 -t)}{\Gamma(n\sigma +1)} \cdot \prod_{j=1}^n  \frac{1}{(1+1/j)^{-t/\sigma}} \prod_{j=n+1}^\infty  \frac{1-\frac{t/\sigma}{j}}{(1+1/j)^{-t/\sigma}} \\
 &=& n^{-t(1-\sigma)/\sigma}   \frac{\Gamma(1-t/\sigma)}{\Gamma(1-t)} \cdot \frac{\Gamma(n\sigma + 1 -t)}{\Gamma(n\sigma +1)} \cdot (1+n)^{t/\sigma} \cdot \prod_{j=n+1}^\infty  \frac{1-\frac{t/\sigma}{j}}{(1+1/j)^{-t/\sigma}}\\
&\approx& n^{-t(1-\sigma)/\sigma}   \frac{\Gamma(1-t/\sigma)}{\Gamma(1-t)} \cdot (n\sigma + 1)^{-t} \cdot (1+n)^{t/\sigma} \cdot \prod_{j=n+1}^\infty  \frac{1-\frac{t/\sigma}{j}}{(1+1/j)^{-t/\sigma}}
\end{array}$$
in the limit for $n \to \infty$
$$\begin{array}{}
\lim_{n \to \infty} E(e^{tS_n})  &=&n^{-t(1-\sigma)/\sigma} \cdot (1+n)^{t/\sigma} \cdot (n\sigma + 1)^{-t} \cdot \frac{\Gamma(1-t/\sigma)}{\Gamma(1-t)} \\
&=& \underbrace {\left( \frac{(1+1/n)^{1/\sigma} }{\sigma + 1/n}\right)^t }_{\to 1/\sigma^t} \cdot \frac{\Gamma(1-t/\sigma)}{\Gamma(1-t)} \\ &=& \frac{\Gamma(1-t/\sigma)}{\sigma^t\Gamma(1-t)}
\end{array}$$
