s23-probability-theory/inputs/lecture_06.tex

\lecture{6}{}{Proof of SLLN}
\begin{refproof}{lln}
    We want to deduce the SLLN (\yaref{lln}) from \yaref{thm2}.
    W.l.o.g.~let us assume that $\bE[X_i] = 0$
    (otherwise define $X'_i \coloneqq  X_i - \bE[X_i]$).
    We will show that $\frac{S_n}{n} \xrightarrow{a.s.} 0$.
    Define $Y_i \coloneqq \frac{X_i}{i}$.
    Then the $Y_i$ are independent and we have $\bE[Y_i] = 0$
    and $\Var(Y_i) = \frac{\sigma^2}{i^2}$.
    Thus $\sum_{i=1}^\infty \Var(Y_i) < \infty$.
    From \yaref{thm2} we obtain that $\sum_{i=1}^\infty Y_i$ converges a.s.
    \begin{claim}
        Let $(a_n)$ be a sequence in $\R$
        such that $\sum_{n=1}^{\infty} \frac{a_n}{n}$ converges,
        then $\frac{a_1 + \ldots + a_n}{n} \to  0$.
    \end{claim}
    \begin{subproof}
        Let $S_m \coloneqq \sum_{n=1}^\infty \frac{a_n}{n}$.
        By assumption, there exists $S \in \R$
        such that $S_m \xrightarrow{m \to \infty} S$.
        Note that $j \cdot (S_{j} - S_{j-1}) = a_j$.
        Define $S_0 \coloneqq  0$.
        Then
        \begin{IEEEeqnarray*}{rCl}
            a_1 + \ldots + a_n &=&
            (S_1 - S_0) + 2(S_2 - S_1) + \ldots + n(S_n - S_{n-1})\\
                               &=& n S_n - (S_1 + S_2 + \ldots + S_{n-1}).
        \end{IEEEeqnarray*}
        Thus
        \begin{IEEEeqnarray*}{rCl}
            \frac{a_1 + \ldots + a_n}{n}
            &=& S_n - \frac{S_1 + \ldots + S_{n-1}}{n}\\
            &=& \underbrace{S_n}_{\to S}
               - \underbrace{\left( \frac{n-1}{n} \right)}_{\mathclap{\to 1}}
                \cdot \underbrace{\frac{S_1 + \ldots +  S_{n-1}}{n-1}}_{\to S}\\
            &\to & 0,
        \end{IEEEeqnarray*}
        where we have used
        \begin{fact}
            \[
            \lim_{n \to \infty} S_n = \lim_{n \to \infty} \frac{1}{n}\sum_{i=1}^{n} S_i
        \].
        \end{fact}
    \end{subproof}
    The SLLN follows from the claim.
\end{refproof}

In order to prove \yaref{thm2}, we need the following:
\begin{theorem}[Kolmogorov's inequality]
    \yalabel{Kolmogorov's Inequality}{Kolmogorov}{thm:kolmogorovineq}
    If $X_1,\ldots, X_n$ are independent with $\bE[X_i] = 0$
    and $\Var(X_i) = \sigma_i^2$, then
    \[
    \bP\left[\max_{1 \le  i \le  n} \left| \sum_{j=1}^{i}  X_j \right| > \epsilon \right]
    \le  \frac{1}{\epsilon^2} \sum_{i=1}^m \sigma_i^2.
    \]
\end{theorem}
\begin{proof}
    Let
    \begin{IEEEeqnarray*}{rCl}
        A_1 &\coloneqq&  \{\omega : |X_1(\omega)| > \epsilon\},\\
        A_2 &\coloneqq & \{\omega: |X_1(\omega)| \le \epsilon,
            |X_1(\omega) + X_2(\omega)| > \epsilon \},\\
        \ldots\\
            A_i &\coloneqq& \{\omega: |X_1(\omega)| \le \epsilon,
                |X_1(\omega) + X_2(\omega)| \le  \epsilon, \ldots, %
                |X_1(\omega) + \ldots + X_{i-1}(\omega)| \le \epsilon,\\
                && ~ ~|X_1(\omega) + \ldots + X_i(\omega)| > \epsilon\}.
    \end{IEEEeqnarray*}
    It is clear, that the $A_i$ are disjoint.
    We are interested in $\bigcup_{1 \le  i \le n} A_i$.

    We have
    \begin{IEEEeqnarray*}{rCl}
        &&\int_{A_i} (\underbrace{X_1 + \ldots + X_i}_C
            + \underbrace{X_{i+1} + \ldots + X_n}_D)^2 \dif\bP\\
        &=& \int_{A_i} C^2 \dif\bP
            + \underbrace{\int_{A_i} D^2 \dif\bP}_{\ge  0}
            + 2 \int_{A_i} CD \dif\bP\\
        &\ge& \int_{A_i}  \underbrace{C^2}_{\ge \epsilon^2} \dif\bP
        + 2 \int \underbrace{\One_{A_i} (X_1 + \ldots + X_i)}_E \underbrace{(X_{i+1} + \ldots + X_n)}_D \dif\bP\\
        &\ge& \int_{A_i} \epsilon^2 \dif\bP,
    \end{IEEEeqnarray*}
    since by the independence of $E$ and $D$,
    and $\bE(X_{i+1}) = \ldots = \bE(X_n) = 0$ we have $\int D E \dif\bP = 0$.

    Hence
    \[
    \bP(A_i)
       \le \frac{1}{\epsilon^2} \int_{A_i} (X_1 + \ldots + X_n)^2 \dif \bP.
    \]
    Since the $A_i$ are disjoint, we obtain
    \begin{IEEEeqnarray*}{rCl}
        \bP\left( \bigcup_{i \in \N} A_i  \right)
        &\le & \frac{1}{\epsilon^2}
        \int_{\bigcup_{i \in \N} A_i} (X_1 + \ldots + X_n)^2 \dif \bP\\
        &\le & \frac{1}{\epsilon^2}
        \int_{\Omega} (X_1 + \ldots + X_n)^2 \dif \bP\\
        &\overset{\text{independence}}{=}&
        \frac{1}{\epsilon^2}(\bE[X_1^2] + \ldots + \bE[X_n^2])\\
        &\overset{\bE[X_i] = 0}{=}& \frac{1}{\epsilon^2}
        \left( \Var(X_1) + \ldots + \Var(X_n)\right).
    \end{IEEEeqnarray*}
\end{proof}

\begin{refproof}{thm2}
    Let $S_n \coloneqq x_1 + \ldots + x_n$.
    We'll show that $\{S_n(\omega)\}_{n \in \N}$
    is a Cauchy sequence
    for almost every $\omega$.

    Let
    \[
    a_m(\omega) \coloneqq  \sup_{k \in \N}
    \{ | S_{ m+k}(\omega) - S_m(\omega)|\}
    \]
    and
    \[
    a(\omega) \coloneqq  \inf_{m \in \N} a_m(\omega).
    \]
    Then $\{S_n(\omega)\}_{n \in \R}$
    is a Cauchy sequence iff $a(\omega) = 0$.

    We want to show that $\bP[a(\omega) > 0] = 0$.
    For this, it suffices to show that $\bP[a(\omega) > \epsilon] = 0$
    for all $\epsilon > 0$.
    For a fixed $\epsilon > 0$, we obtain:
    \begin{IEEEeqnarray*}{rCl}
        \bP[a_m > \epsilon]
        &=& \bP[ \sup_{k \in \N} | S_{m+k} - S_m| > \epsilon]\\
        &=& \lim_{l \to \infty} \bP[%
        \underbrace{\sup_{k \le l} |S_{m+k} - S_m| > \epsilon}_{%
        \text{\reflectbox{$\coloneqq$}} B_l \uparrow%
        B \coloneqq \{\sup_{k \in \N} |S_{m+k} - S_m| > \epsilon\}}%
        ]
    \end{IEEEeqnarray*}

    Now,
    \begin{IEEEeqnarray*}{rCl}
        &&\max \{|S_{m+1} - S_m|, |S_{m+2} - S_m|, \ldots, |S_{m+l} - S_m|\}\\
        &=& \max \{|X_{m+1}|, |X_{m+1} + X_{m+2}|, \ldots, |X_{m+1} + X_{m+2} + \ldots + X_{m+l}|\}\\
        &\overset{\yaref{thm:kolmogorovineq}}{\le}&
        \frac{1}{\epsilon^2} \sum_{i=m}^{l} \Var(X_i)\\
        &\le & \frac{1}{\epsilon^2} \sum_{i=m}^\infty \Var(X_i)
        \xrightarrow{m \to \infty} 0,
    \end{IEEEeqnarray*}
    since by our assumption, $\sum_{n \in \N} \Var(X_i) < \infty$.

    Hence
    \[
    \bP[a_m > \epsilon] \xrightarrow{m \to \infty} 0.
    \]
    It follows that $\bP[a > \epsilon] = 0$,
    as claimed.
\end{refproof}



\subsubsection{Application: Renewal Theorem}

\begin{theorem}[Renewal theorem]
    Let $X_1,X_2,\ldots$ i.i.d.~random variables with $X_i \ge  0$, $\bE[X_i] = m > 0$. The $X_i$ model waiting times.
    Let $S_n \coloneqq  \sum_{i=1}^n X_i$.
    For all $t > 0$ let \[
    N_t \coloneqq  \sup \{n : S_n \le  t\}.
    \]
    Then $\frac{N_t}{t} \xrightarrow{a.s.} \frac{1}{m}$ as $t \to \infty$.
\end{theorem}

    The $X_i$ can be thought of as waiting times.
    $S_i$ models how long you have to wait for $i$ events to occur.

\begin{proof}
    By SLLN, $\frac{S_n}{n} \xrightarrow{a.s.} m$ as $n \to \infty$.
    Note that
    \begin{equation}
        N_t \uparrow \infty \text{ a.s.~as } t \to \infty, \label{eqn:renewalnt}
    \end{equation}
    since $\{N_t \ge  n\} = \{X_1 + \ldots+ X_n \le t\}$.

    \begin{claim}
        $\bP[\frac{S_n}{n} \xrightarrow{n \to \infty} m
            \land N_t \xrightarrow{t \to  \infty}  \infty] = 1$.
    \end{claim}
    \begin{subproof}
    Let $A \coloneqq  \{\omega: \frac{S_n(\omega)}{n} \xrightarrow{n \to  \infty} m\}$
    and $B \coloneqq \{\omega : N_t(\omega) \xrightarrow{t \to  \infty} \infty\}$.
    By the SLLN we have $\bP(A^C) = 0$
    and by \eqref{eqn:renewalnt} it holds that $\bP(B^C) = 0$.
    \end{subproof}

    Equivalently,
    $\bP\left[ \frac{S_{N_t}}{N_t} \xrightarrow{t \to \infty} m
        \land \frac{S_{N_t + 1}}{N_t + 1} \xrightarrow{t \to  \infty} m \right] = 1$.

    By definition, we have $S_{N_t} \le  t \le  S_{N_t + 1}$.
    Thus
    \[\frac{S_{N_t}}{N_t} \le \frac{t}{N_t} \le \frac {S_{N_t + 1}}{N_t}
    \le  \frac{S_{N_t + 1}}{N_t + 1} \cdot  \frac{N_t + 1}{N_t}.\]
    Hence $\frac{t}{N_t} \to  m$.

\end{proof}