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Show that no unbiased estimator exists of \(\psi=\log \\{\pi /(1-\pi)\\}\), based on a binomial variable with probability \(\pi\).

Short Answer

Expert verified
No unbiased estimator exists for \( \psi = \log \left( \frac{\pi}{1-\pi} \right) \) based on a binomial variable.

Step by step solution

01

Define the Problem

We want to determine if there exists an unbiased estimator for \[ \psi = \log \left( \frac{\pi}{1-\pi} \right) \]where \( \pi \) is the probability parameter of a Binomial distribution, and we are working with a binomial random variable \( X \). An estimator is unbiased if the expected value of the estimator equals the parameter it estimates.
02

Consider the Expected Value of an Estimator

Let \( T(X) \) be an unbiased estimator for \( \psi \). This means:\[ E[T(X)] = \psi = \log \left( \frac{\pi}{1-\pi} \right) \]This requires that the expected value of \( T(X) \), a function of the binomially distributed \( X \), exactly equals \( \psi \).
03

Analyze the Expected Value

For a Binomial random variable \( X \sim Bin(n, \pi) \), the possible values of \( X \) are finite \( \{0, 1, 2, ..., n\} \). The expected value is:\[ E[T(X)] = \sum_{x=0}^{n} T(x) \binom{n}{x} \pi^x (1-\pi)^{n-x} \]We need this expression to hold for all \( \pi \) and result in \( \log \left( \frac{\pi}{1-\pi} \right) \).
04

Explore Feasibility

The requirement is that \( E[T(X)] \) yields \( \log \left( \frac{\pi}{1-\pi} \right) \) for any \( \pi \). This is challenging as \( \psi \) is a nonlinear transformation of \( \pi \).\[ \psi \] maps \( (0, 1) \rightarrow (-\infty, \infty) \), which makes it difficult to find a \( T(x) \) that translates \( X \) into this range directly without bias.
05

Conclude Non-existence of Estimator

Given the nonlinearity and the nature of logarithmic transformation involved, coupled with the finite support of \( X \), it's not feasible to form a single \( T(X) \) function so that its expectation across all \( \pi \) respects \( E[T(X)] = \log \left( \frac{\pi}{1-\pi} \right) \) for all \( \pi \). Therefore, no unbiased estimator can exist under these conditions.

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Key Concepts

These are the key concepts you need to understand to accurately answer the question.

Binomial Distribution
The Binomial Distribution is fundamental in probability and statistics, often used to model scenarios where there are only two possible outcomes. These outcomes are commonly referred to as 'success' and 'failure'. The distribution describes the number of successes in a fixed number of independent Bernoulli trials, each with the same probability of success, denoted by \( \pi \). When working with binomial variables, it's important to remember:
  • The distribution is discrete, meaning it can only take on whole number values within the range \( \{0, 1, 2, ..., n\} \).
  • Each trial in a Binomial setting is independent, ensuring that the outcome of one trial does not affect another.
  • The probability of success, \( \pi \), remains constant across trials.
The binomial random variable \( X \) representing the total number of successes follows the binomial distribution's probability mass function:\[ P(X = k) = \binom{n}{k} \pi^k (1-\pi)^{n-k} \]Here, \( \binom{n}{k} \) represents the number of ways to choose \( k \) successes from \( n \) trials. This makes the Binomial distribution highly versatile and a go-to model for binary outcome experiments.
Logarithmic Transformation
The logarithmic transformation is an exceptional tool used in statistics to analyze data, especially when dealing with multiplicative relationships or skewed data. By applying a logarithm, we can linearize non-linear relationships, stabilize variance, and make the interpretations of data easier. In the context of the given exercise, the transformation is applied to the probability parameter \( \pi \) of the binomial distribution. Here is how it is used:For the function \( \psi = \log \left( \frac{\pi}{1-\pi} \right) \), the transformation converts the odds of success in a binary outcome scenario into a real number that spans the entire range of real numbers, \( (-\infty, \infty) \). This range makes the manipulation and analysis of the parameter more flexible but also introduces complexity in finding unbiased estimators. Key benefits of logarithmic transformations include:
  • Converting exponential growth patterns to linear, aiding in easier analysis and modeling.
  • Handling wide ranges of data by reducing the effect of outliers.
  • Transforming data into approximately normal distribution, a prerequisite for many statistical tests.
Understanding logarithmic transformations helps simplify complex relationships in data, although it demands careful consideration of its impacts on interpretability.
Expected Value
Expected Value is a core concept in statistics that refers to the long-term average or mean of a random variable over numerous trials. It essentially provides a measure of the center of the distribution for the random variable. Mathematically, it is expressed as:For a continuous random variable: \[ E[X] = \int_{-\infty}^{\infty} x f(x) \, dx \]For a discrete random variable:\[ E[X] = \sum_{x} x P(X = x) \]In the binomial context, it simplifies due to the finite number of possible outcomes. The expected value of a binomially distributed random variable \( X \sim Bin(n, \pi) \) is given by:\[ E[X] = n\pi \]When looking for an unbiased estimator, such as in the exercise, the expected value of the estimator should exactly equal the parameter being estimated. This makes expected value crucial because it quantifies the requirement for unbiasedness: The expected value of the estimator \( T(X) \) must satisfy:\[ E[T(X)] = \psi \]This requirement complicates matters, especially when the parameter involves nonlinear transformations like the logarithmic transformation. Understanding expected values assures you properly evaluate estimators and their precision in reflecting the true parameter values over numerous applications.

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Most popular questions from this chapter

If \(U \sim U(0,1)\), show that \(\min (U, 1-U) \sim U\left(0, \frac{1}{2}\right)\). Hence justify the computation of a two-sided significance level as \(2 \min \left(P^{-}, P^{+}\right)\).

Let \(\bar{Y}\) be the average of a random sample from the uniform density on \((0, \theta)\). Show that \(2 \bar{Y}\) is unbiased for \(\theta\). Find a sufficient statistic for \(\theta\), and obtain an estimator based on it which has smaller variance. Compare their mean squared errors.

(a) Let \(Y_{1}, \ldots, Y_{n}\) be a random sample from the exponential density \(\lambda e^{-\lambda y}, y>0, \lambda>0\) Say why an unbiased estimator \(W\) for \(\lambda\) should have form \(a / S\), and hence find \(a\). Find the Fisher information for \(\lambda\) and show that \(\mathrm{E}\left(W^{2}\right)=(n-1) \lambda^{2} /(n-2)\). Deduce that no unbiased estimator of \(\lambda\) attains the Cramér-Rao lower bound, although \(W\) does so asymptotically. (b) Let \(\psi=\operatorname{Pr}(Y>a)=e^{-\lambda a}\), for some constant \(a\). Show that $$ I\left(Y_{1}>a\right)= \begin{cases}1, & Y_{1}>a \\ 0, & \text { otherwise }\end{cases} $$ is an unbiased estimator of \(\psi\), and hence obtain the minimum variance unbiased estimator. Does this attain the Cramér-Rao lower bound for \(\psi\) ?

Let \(R\) be binomial with probability \(\pi\) and denominator \(m\), and consider estimators of \(\pi\) of form \(T=(R+a) /(m+b)\), for \(a, b \geq 0\). Find a condition under which \(T\) has lower mean squared error than the maximum likelihood estimator \(R / m\), and discuss which is preferable when \(m=5,10\).

Find the optimal estimating function based on dependent data \(Y_{1}, \ldots, Y_{n}\) with \(g_{j}(Y ; \theta)=\) \(Y_{j}-\theta Y_{j-1}\) and \(\operatorname{var}\left\\{g_{j}(Y ; \theta) \mid Y_{1}, \ldots, Y_{j-1}\right\\}=\sigma^{2} .\) Derive also the estimator \(\tilde{\theta}\). Find the maximum likelihood estimator of \(\theta\) when the conditional density of \(Y_{j}\) given the past is \(N\left(\theta y_{j-1}, \sigma^{2}\right) .\) Discuss.

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