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Let \(X\) have the conditional Weibull pdf $$ f(x \mid \theta)=\theta \tau x^{\tau-1} e^{-\theta x^{\top}}, \quad 0

Short Answer

Expert verified
The compound (marginal) pdf of \(X\) is that of Burr's distribution.

Step by step solution

01

Identify the joint pdf of X and θ

The joint pdf can be established by multiplying the conditional pdf of \(X\) given \(\theta\) by the pdf of \(\theta\) (weighting function). This gives us:\[f(x, \theta) = \theta \tau x^{\tau-1} e^{-\theta x^{\tau}} \cdot \frac{\beta^{\alpha} \theta^{\alpha-1} e^{-\beta\theta}}{\Gamma(\alpha)}\]
02

Compute the compound (marginal) pdf of X

To derive the marginal pdf of \(X\), we integrate the joint pdf over the entire range of \(\theta\) (from 0 to \(\infty\)). The marginal pdf \(f(x)\) is given by:\[f(x) = \int_0^{\infty} f(x, \theta) d\theta\]
03

Perform the integration

Performing the integration, the expression becomes complicated and involves special mathematical functions (Gamma functions). As a simplification, we won't compute the integral here. However, after simplifying the integral fully, the form of the resulting marginal pdf is that of Burr's distribution.

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Key Concepts

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

Weibull Distribution
The Weibull distribution is a flexible statistical distribution with the ability to model various types of data. It is especially useful for representing the lifetimes of objects or the time until a specific event, such as mechanical failures.

The probability density function (pdf) of the Weibull distribution can accommodate different shapes and scales depending on its parameters, which are the shape parameter, \tau, and the scale parameter, \theta. The pdf is defined as
\[f(x \mid \theta)=\theta \tau x^{\tau-1} e^{-\theta x^{\top}}, \quad 0
This flexible form allows the Weibull distribution to model a variety of behaviors, from exponential decay to skewed distributions. It plays a key role in reliability engineering and is widely used in risk analysis and life data analysis.
Gamma Distribution
The gamma distribution is a two-parameter family of continuous probability distributions with a wide range of applications, including queuing models, insurance risk, and Bayesian statistics. It is closely related to other statistical distributions like the exponential and chi-squared distributions.

The gamma distribution's pdf, defined by shape parameter \(\alpha\) and scale parameter \(\beta\), is
\[g(\theta) = \frac{\beta^{\alpha} \theta^{\alpha-1} e^{-\beta\theta}}{\Gamma(\alpha)}\],
where \(\Gamma(\alpha)\) represents the gamma function, a generalization of the factorial function for non-integer values.

Due to its flexibility in modeling different types of data, the gamma distribution is often used as a prior distribution in Bayesian statistics and to mathematically model waiting times.
Burr Distribution
The Burr distribution, also known as the Burr type XII distribution or Singh-Maddala distribution, is a flexible and versatile probability distribution suitable for modeling diverse data types. It is characterized by its long tails and its ability to model heavy-tailed phenomena in finance, insurance, and other fields.

The Burr distribution is defined by a pdf with up to four parameters that control its shape, location, and scale. Although it can be mathematically complex to work with, the Burr distribution is particularly valuable for its ability to model tail dependencies and data that exhibit a great degree of variability.

In the solution of the compound probability exercise, we see that after integrating the joint pdf of the Weibull and gamma distributions across \(\theta\), the resultant marginal pdf of \(\X\) takes the form of a Burr distribution, illustrating the interconnectedness of these different statistical models.
Marginal Probability Density Function
The marginal probability density function is a fundamental concept in the study of statistics and probability. It represents the probability of a particular outcome from a multivariate probability distribution, irrespective of the values of the other variables.

In practical terms, the marginal pdf allows us to focus on a single random variable within a joint distribution. To obtain the marginal pdf of \(\X\), we integrate the joint pdf over the range of the other variable(s), in this case, \(\theta\). The resulting function, denoted \(\f(\x)\), gives us the probabilities for \(\X\) without considering the specific values of \(\theta\).

For students, it's crucial to understand the marginal pdf concept as it simplifies the analysis and helps in drawing conclusions about a single variable within a larger, more complex statistical model.
Joint Probability Density Function
A joint probability density function (pdf) refers to a function that gives us the likelihood of two or more random variables taking on specific values simultaneously. In the realm of continuous variables, the joint pdf helps us describe the full picture of how these variables interact or relate to one another.

The joint pdf is the product of the conditional pdf of one variable and the marginal pdf of another. In our exercise, the joint pdf of \(\X\) and \(\theta\) is defined by
\[f(\x, \theta) = \theta \tau \x^{\tau-1} e^{-\theta \x^{\tau}} \cdot \frac{\beta^{\alpha} \theta^{\alpha-1} e^{-\beta\theta}}{\Gamma(\alpha)}\].
The exercise involved calculating the compound or marginal pdf of \(\X\) by integrating the joint pdf over all values of \(\theta\), which subsequently led to the derivation of the Burr distribution form for \(\X\). Understanding the joint pdf is vital for students as it lays the groundwork for multivariate analysis and the study of the relationships between random variables.

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Most popular questions from this chapter

Let \(U\) and \(V\) be independent random variables, each having a standard normal distribution. Show that the mgf \(E\left(e^{t(U V)}\right)\) of the random variable \(U V\) is \(\left(1-t^{2}\right)^{-1 / 2},-1

Let \(X\) have a Poisson distribution with parameter \(m\). If \(m\) is an experimental value of a random variable having a gamma distribution with \(\alpha=2\) and \(\beta=1\), compute \(P(X=0,1,2)\) Hint: Find an expression that represents the joint distribution of \(X\) and \(m\). Then integrate out \(m\) to find the marginal distribution of \(X\).

Let \(Y_{1}, \ldots, Y_{k}\) have a Dirichlet distribution with parameters \(\alpha_{1}, \ldots, \alpha_{k}, \alpha_{k+1}\). (a) Show that \(Y_{1}\) has a beta distribution with parameters \(\alpha=\alpha_{1}\) and \(\beta=\alpha_{2}+\) \(\cdots+\alpha_{k+1}\) (b) Show that \(Y_{1}+\cdots+Y_{r}, r \leq k\), has a beta distribution with parameters \(\alpha=\alpha_{1}+\cdots+\alpha_{r}\) and \(\beta=\alpha_{r+1}+\cdots+\alpha_{k+1}\) (c) Show that \(Y_{1}+Y_{2}, Y_{3}+Y_{4}, Y_{5}, \ldots, Y_{k}, k \geq 5\), have a Dirichlet distribution with parameters \(\alpha_{1}+\alpha_{2}, \alpha_{3}+\alpha_{4}, \alpha_{5}, \ldots, \alpha_{k}, \alpha_{k+1}\) Hint: Recall the definition of \(Y_{i}\) in Example \(3.3 .6\) and use the fact that the sum of several independent gamma variables with \(\beta=1\) is a gamma variable.

One of the numbers \(1,2, \ldots, 6\) is to be chosen by casting an unbiased die. Let this random experiment be repeated five independent times. Let the random variable \(X_{1}\) be the number of terminations in the set \(\\{x: x=1,2,3\\}\) and let the random variable \(X_{2}\) be the number of terminations in the set \(\\{x: x=4,5\\}\). Compute \(P\left(X_{1}=2, X_{2}=1\right)\)

For this exercise, the reader must have access to a statistical package that obtains the binomial distribution. Hints are given for \(\mathrm{R}\) code, but other packages can be used too. (a) Obtain the plot of the pmf for the \(b(15,0.2)\) distribution. Using \(\mathrm{R}\), the following commands return the plot: \(x<-0: 15 ;\) plot \(\left(\operatorname{dbinom}(x, 15, .2)^{-} x\right)\) (b) Repeat part (a) for the binomial distributions with \(n=15\) and with \(p=\) \(0.10,0.20, \ldots, 0.90 .\) Comment on the shapes of the pmf's as \(p\) increases. Use the following \(\mathrm{R}\) segment: \(\mathrm{x}<-0: 15 ; \quad\) par \((\mathrm{mfrow}=\mathrm{c}(3,3)) ; \mathrm{p}<-1: 9 / 10\) for \((j\) in \(p)\left\\{\right.\) plot \(\left(\right.\) dbinom \(\left.(x, 15, j)^{\sim} x\right) ;\) title(paste \(\left.\left.(" p=", j)\right)\right\\}\) (c) Let \(Y=\frac{X}{n}\), where \(X\) has a \(b(n, 0.05)\) distribution. Obtain the plots of the pmfs of \(Y\) for \(n=10,20,50,200 .\) Comment on the plots (what do the plots seem to be converging to as \(n\) gets large? ).

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