Jump to Problem 2,3

Problem 3

Problem statement: 

Let $ \mathbf{X}_{1} \dots \mathbf{X}_{n} \dots $ be a sequence of independent, identical distributed random variables, each uniformly distributed on the interval [0, 1], an hence having pdf
$ f_{X}\left(x\right)=\begin{cases} \begin{array}{lll} 1, \text{ for } 0 \leq x \leq1\\ 0, \text{ elsewhere. } \end{array}\end{cases} $

Let $ \mathbf{Y}_{n} $ be a new random variable defined by

$ \mathbf{Y}_{n} = min \,\{{ \mathbf{X}_1, \mathbf{X}_2, \dots \mathbf{X}_n} \} $

(a) Find the pdf of $ \mathbf{Y}_{n} $.

(b) Does the sequence $ \mathbf{Y}_{n} $ converge in probability?

(c) Does the sequence $ \mathbf{Y}_{n} $ converge in distribution? If yes, specify the cumulative function of the random variable it converges to.

$ \color{blue}\text{Solution 1:} $

$ f_{X}(x) = 1_{[0,1]}(x) = \left\{ \begin{array}{ll} 1 & \quad 0 \leq x \leq 1 \\ 0 & \quad elsewhere \end{array} \right. $

$ F_{X}(x) = \int_0^x f_{X}(\alpha)d\alpha = \int_0^x d\alpha = x $

Y_n = m'i'n{X₁,....,X_n}

(a)

$ \; \; \; F_{Y_{n}}(y) = P(\{Y \leq y\}) $
$ = P(\{min\{X_{1}, ..., X_{n}\} \leq y\}) $

= 1 − P({X₁ > y},....,{X_n > y})

= 1 − P({X₁ > y})P({X₂ > y})...P({X_n > y})

= 1 − (1 − y)ⁿ

$ f_{Y_{n}}(y) = \frac{dF_{Y}(y)}{dy} = n(1-y)^{n-1} 1_{[0, 1]}(y) $

(b)

Yes. It converges in probability.

A random variable converges in probability if

$ P\{\mid Y_{n} - a \mid > \varepsilon\} \rightarrow 0 \;\; as \; n \rightarrow \inf \;\; for \;any\; \varepsilon > 0 $

Then the random variable is said to converge to a.

Consider

$ P\{\mid Y_{n}-0 \mid > \varepsilon\} = P\{Y_{n}>\varepsilon\} $

$ = 1 - P\{Y_{n} \leq \varepsilon\} = 1 - [1-(1-\varepsilon)^n] = (1-\varepsilon)^n $

$ As\; n\rightarrow \inf \; \; \; P\{\mid Y_{n}-0 \mid > \varepsilon\} = 0 $

Since $ 0 < (1-\varepsilon) <1 $

Thus $ Y_{n} \rightarrow 0 $

(c)

From the solution to (a), we have

$ F_{Y_{n}}(y) = \left\{ \begin{array}{ll} 1 - (1-y)^{n} & \quad 0 < y \leq 1 \\ 1 & \quad y > 1 \end{array} \right. $

It converges in distribution since:
$ convergence(probability) \Rightarrow convergence(distribution) $

To find the convergence of CDF,
$ \lim_{n \to \infty} F_{Y_{n}}(y) = \left\{ \begin{array}{ll} 0 & \quad y \leq 0 \\ \lim_{n \to \infty} 1 - (1-y)^{n} & \quad 0 < y \leq 1 \\ 1 & \quad y > 1 \end{array} \right. = \left\{ \begin{array}{ll} 0 & \quad y \leq 0 \\ 1 & \quad y > 0 \end{array} \right. $

$ {\color{red} \text{*For part (a), there is a typo for the following equation}} $

$ {\color{red} F_{Y_{n}}(y) = P(\{Y \leq y\}) = P(min\{X_{1}, \dots, X_{n}\} \leq y) \text{, and should be changed to} } $

$ {\color{red} F_{Y_{n}}(y) = P(\{Y_{n} \leq y\}) = P(min\{X_{1}, \dots, X_{n}\} \leq y) } $

$ {\color{red} \text{*For part (b), I would like to add some additional parts to the following equation for better understanding}} $

$ {\color{red} n\rightarrow \inf \; \; \; P\{\mid Y_{n}-0 \mid > \varepsilon\} = 0} $

$ {\color{red} \text{Since } 0 < (1-\varepsilon) <1} $

$ {\color{red} \text{to }} $

$ {\color{red}\text{Since } 0 < (1-\varepsilon) <1 \text{, as } n\rightarrow \infty \Rightarrow \lim_{n \to \infty}(1-\varepsilon)^n = 0 \; \; \; \therefore \lim_{n \to \infty}P\{\mid Y_{n}-0 \mid > \varepsilon\} = \lim_{n \to \infty} (1-\varepsilon)^n = 0} $

$ {\color{red} \text{*For part (c), the CDF of the random variable } \mathbf{Y}_n \text{ is incorrect. It should be}} $

$ {\color{red} F_{Y_n}\left(y\right)=\begin{cases} \begin{array}{lll} 0, y <0 \\ 1-(1-y)^n, 0 \leq y \leq 1 \\ 1, y>1 \end{array}\end{cases} } $

$ {\color{red} \text{Therefore, it should be modified as follow}} $

$ {\color{red} \text{As } n \to \infty \text{,} \,\, F_{Y_n}(y) \to F_{Y}(y)=\begin{cases} \begin{array}{lll} 0, y <0 \\ 1, y \geq 0 \end{array}\end{cases} } $

$ \color{blue}\text{Solution 2:} $

(a)
Since $ \mathbf{Y}_{n} = min \,\{{ \mathbf{X}_1, \mathbf{X}_2, \dots \mathbf{X}_n} \} $, and $ \{{ \mathbf{X}_1, \mathbf{X}_2, \dots \mathbf{X}_n} \} $ are i.i.d R.V.
We can have the CDF of $ \mathbf{Y}_{n} $
$ P(\mathbf{Y}_{n} \leq y) = P(\,\{{ \mathbf{X}_1, \mathbf{X}_2, \dots \mathbf{X}_n} \} \leq y) $
$ = 1-P(\,\{{ \mathbf{X}_1, \mathbf{X}_2, \dots \mathbf{X}_n} \} > y) $
$ = 1-P(\mathbf{X}_1 > y)P(\mathbf{X}_2 > y) \dots P(\mathbf{X}_n > y) $
$ = 1-(1-F_{X_1}(y))(1-F_{X_2}(y)) \dots (1-F_{X_n}(y))=1-(1-F_{X_1}(y))^n $

Since $ \mathbf{Y}_{n} $ is also uniform distributed on the interval [0,1]
When Y_n = y < 0, $ P(\{\mathbf{Y}_{n}<0 \}) =0 $ since $ F_{X_1}(y) =0 $
When Y_n = y > 1, $ P(\{\mathbf{Y}_{n}>1 \}) =1 $ since $ F_{X_1}(y) =1 $
When $ 0 \leq Y_n = y \leq 1 $

$ F_{X_1}(y)= \int_{0}^{y}f_{X_1}(x)\,dx=\int_{0}^{y}\, 1 \, dx = y $

Thus, the CDF of $ \mathbf{Y}_{n} $ is the following
$ F_{Y_n}\left(y\right)=\begin{cases} \begin{array}{lll} 0, y <0 \\ 1-(1-y)^n, 0 \leq y \leq 1 \\ 1, y>1 \end{array}\end{cases} $
Thus, the pdf of $ \mathbf{Y}_{n} $ is
$ f_{Y_n}\left(y\right)=\begin{cases} \begin{array}{lll} n(1-y)^{n-1}, 0 \leq y \leq 1 \\ 0, \,\,\, \text{elsewhere} \end{array}\end{cases} $

(b)
Let μ = E[Y_n] and σ² = E( | Y_n − μ | ²). By Chebyshev inequality, we have
$ P(|\mathbf{Y}_{n}-\mu| \geq \varepsilon) \leq \frac{\sigma^2}{\varepsilon^2} = \frac{E[|\mathbf{Y}_{n}-\mu|^2]}{\varepsilon^2} $
Now, we examine
$ E[|\mathbf{Y}_{n}-\mu|^2] = E[Y_n^2-2 \mu Y_n+\mu^2] = E[Y_n^2]-2\mu E[Y_n]+\mu^2=E[Y_n^2]-\mu^2. $

In problem (a), we have the pdf of Y_n, we can find E[Y_n] and $ E[Y_n^2] $
$ E[Y_n] = \int_{0}^{1}y f_{Y_n}(y) \,dy = \int_{0}^{1} y n(1-y)^{n-1} \, dy = \frac{1}{n+1} $
$ E[Y_n^2] = \int_{0}^{1}y^2 f_{Y_n}(y) \,dy = \int_{0}^{1} y^2 n(1-y)^{n-1} \, dy = \frac{2}{n^2+3n+2} $
As $ n \to \infty $
$ \lim_{n \to \infty} E[|\mathbf{Y}_{n}-\mu|^2] = \lim_{n \to \infty} \left( E[Y_n^2]-(E[Y_n])^2 \right)= \lim_{n \to \infty}\left( \frac{2}{n^2+3n+2}- (\frac{1}{n+1})^2\right)=0 $
$ \Rightarrow P(|\mathbf{Y}_{n}-\mu| \geq \varepsilon) \leq \frac{E[|\mathbf{Y}_{n}-\mu|^2]}{\varepsilon^2} = 0 \,\,\text{as} \,n \to \infty $
Thus, the sequence Y_n converges in probability to μ for any $ \varepsilon>0 $, and
$ \lim_{n \to \infty} \mu = \lim_{n \to \infty} E[Y_{n}] = \lim_{n \to \infty} \frac{1}{n+1} =0 $
$ \therefore P(|\mathbf{Y}_{n}-\mu| \geq \varepsilon) = P(|\mathbf{Y}_{n}-0| \geq \varepsilon) \to 0 \,\,\text{as} \,\, n \to \infty $

(c)
The CDF of Y_n
$ F_{Y_n}\left(y\right)=\begin{cases} \begin{array}{lll} 0, y <0 \\ 1-(1-y)^n, 0 \leq y \leq 1 \\ 1, y>1 \end{array}\end{cases} $

As $ n \to \infty $
$ F_{Y_n}(y) \to F_{Y}(y)= \begin{cases} \begin{array}{lll} 0, \,\, y <0 \\ 1, \,\, y \geq 0 \end{array}\end{cases} $
where $ 1-(1-y)^n \to 1 $ as $ n \to \infty $, when 0 < y < 1
Because 0 < (1 − y) < 1, $ (1-y)^n \to 0 $, when $ n \to \infty $
$ F_{Y}(y)= \begin{cases} \begin{array}{lll} 0, \,\, y <0 \\ 1, \,\, y \geq 0 \end{array}\end{cases} $
where this CDF is a step function.

Thus, the sequence of random variable Y_n with cumulative distribution function $ F_{Y_n}(y) $ converges in distribution to the random variable Y with cumulative distribution function F_Y(y), which is a step function.

Comments on Solution 2:

1. Curly braces are required to take probabilities on events.

2. Error in part (c): As n grows to infinity, 1 - (1-y)ⁿ is definitely not equal to 1, for y = 0. Technically, that would lead to an indeterminate value at y = 0, or can be thought of to be 0 (as engineering common practice).

Related Problems

1. Let X_n be a sequence of independent, identical distributed random variables, each has Cauchy pdf
$ f(x)=\frac{1}{\pi (1+x^2)} \text{, } -\infty < x < \infty $

Let Y_n a new random variable defined by
$ Y_{n} = \frac{1}{n} \sum_{i=1}^{n} \, X_{i} $

(a) Find the pdf of the sequence Y_n, and describe how it depends on n.

(b) Does the sequence $ \mathbf{Y}_{n} $ converge in distribution?

(c) If yes, what is the distribution of the random variable it converges to?

2. Explain what happens in this problem when:

(a) Y_n = max{X₁, X₂, ...., X_n}.

(b) X₁, X₂, ...., X_n are exponentially distributed.