OCR MEI S4 2014 June — Question 2 24 marks

Exam BoardOCR MEI
ModuleS4 (Statistics 4)
Year2014
SessionJune
Marks24
PaperDownload PDF ↗
Mark schemeDownload PDF ↗
TopicThe Gamma Distribution
TypeDeriving moment generating function
DifficultyChallenging +1.2 This is a structured Further Maths Statistics question requiring derivation of an MGF through integration, then applying MGF properties and transformations. Part (i) requires integration by substitution/recognition of gamma function form (moderately technical but standard for S4). Parts (ii)-(iv) are routine applications of MGF theory (sums, linear transformations, distribution identification). Part (v) requires finding expected length using E[W] from the MGF. While multi-step and requiring several techniques, each component is a standard application of taught material with clear signposting—typical of a structured Further Maths statistics question rather than requiring novel insight.
Spec5.03a Continuous random variables: pdf and cdf5.04a Linear combinations: E(aX+bY), Var(aX+bY)5.05d Confidence intervals: using normal distribution

2
  1. The probability density function of the random variable \(X\) is $$\mathrm { f } ( x ) = \frac { x ^ { k - 1 } \mathrm { e } ^ { - x / \phi } } { \phi ^ { k } ( k - 1 ) ! } , x > 0$$ where \(k\) is a known positive integer and \(\phi\) is an unknown parameter ( \(\phi > 0\) ). Show that the moment generating function (mgf) of \(X\) is $$\mathrm { M } _ { X } ( \theta ) = ( 1 - \phi \theta ) ^ { - k }$$ for \(\theta < \frac { 1 } { \phi }\).
  2. Write down the mgf of the random variable \(W = \sum _ { i = 1 } ^ { n } X _ { i }\) where \(X _ { 1 } , X _ { 2 } , \ldots , X _ { n }\) are independent random variables each with the same distribution as \(X\).
  3. Write down the mgf of the random variable \(Y = \frac { 2 W } { \phi }\). Given that the mgf of the random variable \(V\) having the \(\chi _ { m } ^ { 2 }\) distribution is \(\mathrm { M } _ { V } ( \theta ) = ( 1 - 2 \theta ) ^ { - m / 2 }\) (for \(\theta < \frac { 1 } { 2 }\) ), deduce the distribution of \(Y\).
  4. Deduce that \(\mathrm { P } \left( l < \frac { 2 W } { \phi } < u \right) = 0.95\) where \(l\) and \(u\) are the lower and upper \(2 \frac { 1 } { 2 } \%\) points of the \(\chi _ { 2 n k } ^ { 2 }\) distribution. Hence deduce that a \(95 \%\) confidence interval for \(\phi\) is given by \(\left( \frac { 2 w } { u } , \frac { 2 w } { l } \right)\) where \(w\) is an observation on the random variable \(W\).
  5. For the case \(k = 2\) and \(n = 10\), use percentage points of the \(\chi ^ { 2 }\) distribution to write down, in terms of \(w\), an expression for a \(95 \%\) confidence interval for \(\phi\). By considering the \(\operatorname { mgf }\) of \(W\), find in terms of \(\phi\) the expected length of this interval.

Question 2:
Part (i)
AnswerMarks Guidance
AnswerMarks Guidance
\(M_X(\theta) = E\ e^{\theta x} = \int_0^\infty \frac{e^{\theta x - \frac{x}{\phi}} x^{k-1}}{\phi^k\ k-1\ !} dx\)M1 Correct integral with attempt to integrate by parts.
\(= \frac{1}{\phi^k\ k-1\ !}\left[\left[x^{k-1} \frac{e^{\theta x - \frac{x}{\phi}}}{\theta - \frac{1}{\phi}}\right]_0^\infty - \int_0^\infty \frac{e^{\theta x - \frac{x}{\phi}}}{\theta - \frac{1}{\phi}}\ k-1\ x^{k-2} dx\right]\)A1 B1 A1 A1 for first term in integral by parts. B1 for sight of first term with limits. A1 for second term in integral by parts.
\(= \frac{1}{\phi^k\ k-1\ !} \cdot \frac{\phi\ k-1}{1-\phi\theta} \int_0^\infty e^{\theta x - \frac{x}{\phi}} x^{k-2} dx\)M1 M1 M1 for re-arrangement into form that re-creates same form as original integral with \(k-2\) instead of \(k-1\). M1 for attempt at "reduction formula" method.
\(= \frac{1}{\phi^k\ k-1\ !} \cdot \frac{\phi^2\ k-1\ k-2}{(1-\phi\theta)^2} \int_0^\infty e^{\theta x - \frac{x}{\phi}} x^{k-3} dx\)
\(= \frac{1}{\phi^k\ k-1\ !} \cdot \frac{\phi^{k-1}\ k-1\ k-2\ \ldots 1}{(1-\phi\theta)^{k-1}} \int_0^\infty e^{\theta x - \frac{x}{\phi}} x^0 dx\)A1 A1 A1 A1 for power \(k-1\) of \(\phi\) in numerator. A1 for \((k-1)(k-2)\ldots 1\) in numerator. A1 for power \(k-1\) of \((1-\phi\theta)\) in denominator. Final integral and integration explicit for following marks (AG).
The integral on the previous line is \(\left[\frac{e^{\theta x - \frac{x}{\phi}}}{\theta - \frac{1}{\phi}}\right]_0^\infty\)M1 A1 M1 for attempt to deal with the \(k=0\) term. A1 for \(\frac{\phi}{1-\phi\theta}\) (may be implicit).
\(= \frac{1}{\phi^k\ k-1\ !} \cdot \frac{\phi^k\ k-1\ !}{(1-\phi\theta)^k} = (1-\phi\theta)^{-k}\)A1 Beware printed answer.
[12]
Part (ii)
AnswerMarks Guidance
AnswerMarks Guidance
\(M_W(\theta) = (1-\phi\theta)^{-nk}\)B1
[1]
Part (iii)
AnswerMarks Guidance
AnswerMarks Guidance
\(M_Y(\theta) = \left(1 - \frac{2\phi\theta}{\phi}\right)^{-nk} = (1-2\theta)^{-nk}\)B1
This is mgf of \(\chi^2_{2nk}\), so by inversion theorem/uniqueness property, distribution of \(Y\) is \(\chi^2_{2nk}\).M1 B1 For some allusion to inversion theorem/uniqueness property. May be awarded for correct conclusion even if preceding M1 was not awarded.
[3]
Part (iv)
AnswerMarks Guidance
AnswerMarks Guidance
We have \(\frac{2W}{\phi} \sim \chi^2_{2nk}\), and \(0.95 = P\left(l < \chi^2_{2nk} < u\right)\) Must link 0.95, \(\chi^2_{2nk}\) to \(l\) and \(u\), thence to \(Y = \frac{2W}{\phi}\). (AG)
\(\therefore 0.95 = P\left(l < \frac{2W}{\phi} < u\right)\)
Inserting an observed value \(w\) of \(W\) gives \(2w/u < \phi\) and \(2w/l > \phi\) so that a 95% confidence interval for \(\phi\) is \((2w/u,\ 2w/l)\).B2,1,0 Final CI must not be embedded in a probability statement.
[2]
Part (v)
AnswerMarks Guidance
AnswerMarks Guidance
We have \(\chi^2_{40}\).B1 Follow-through from here if not 40 d.f.
Confidence interval is \(\left(\frac{2w}{59.34},\ \frac{2w}{24.43}\right)\)A1 Both critical points correct, using candidate's d.f.
We need \(E(W)\). Mgf of \(W\) is \(M_W(\theta) = (1-\phi\theta)^{-20}\) (see part (ii)).M1 For realising \(E(W)\) is needed. \(nk = 20\) may be seen below.
\(E(W) = M'(0)\).M1 For attempt to find first derivative at zero, or by expanding the series.
\(M'(\theta) = -20(1-\phi\theta)^{-21}(-\phi)\) \(\therefore M'(0) = 20\phi\)A1
\(\therefore E(\text{length of CI}) = \frac{2 \times 20\phi}{24.43} - \frac{2 \times 20\phi}{59.34}\)A1 cao (no follow-through from candidate's incorrect d.f.)
\(= 40\phi(0.040933 - 0.016852) = 40\phi(0.0240812) = 0.963(25)\phi\) Usual penalty for over-specification of final answer. (3 or 4 sf, awrt 0.963)
[6]
# Question 2:

## Part (i)

| Answer | Marks | Guidance |
|--------|-------|----------|
| $M_X(\theta) = E\ e^{\theta x} = \int_0^\infty \frac{e^{\theta x - \frac{x}{\phi}} x^{k-1}}{\phi^k\ k-1\ !} dx$ | M1 | Correct integral with attempt to integrate by parts. |
| $= \frac{1}{\phi^k\ k-1\ !}\left[\left[x^{k-1} \frac{e^{\theta x - \frac{x}{\phi}}}{\theta - \frac{1}{\phi}}\right]_0^\infty - \int_0^\infty \frac{e^{\theta x - \frac{x}{\phi}}}{\theta - \frac{1}{\phi}}\ k-1\ x^{k-2} dx\right]$ | A1 B1 A1 | A1 for first term in integral by parts. B1 for sight of first term with limits. A1 for second term in integral by parts. |
| $= \frac{1}{\phi^k\ k-1\ !} \cdot \frac{\phi\ k-1}{1-\phi\theta} \int_0^\infty e^{\theta x - \frac{x}{\phi}} x^{k-2} dx$ | M1 M1 | M1 for re-arrangement into form that re-creates same form as original integral with $k-2$ instead of $k-1$. M1 for attempt at "reduction formula" method. |
| $= \frac{1}{\phi^k\ k-1\ !} \cdot \frac{\phi^2\ k-1\ k-2}{(1-\phi\theta)^2} \int_0^\infty e^{\theta x - \frac{x}{\phi}} x^{k-3} dx$ | | |
| $= \frac{1}{\phi^k\ k-1\ !} \cdot \frac{\phi^{k-1}\ k-1\ k-2\ \ldots 1}{(1-\phi\theta)^{k-1}} \int_0^\infty e^{\theta x - \frac{x}{\phi}} x^0 dx$ | A1 A1 A1 | A1 for power $k-1$ of $\phi$ in numerator. A1 for $(k-1)(k-2)\ldots 1$ in numerator. A1 for power $k-1$ of $(1-\phi\theta)$ in denominator. Final integral and integration explicit for following marks (AG). |
| The integral on the previous line is $\left[\frac{e^{\theta x - \frac{x}{\phi}}}{\theta - \frac{1}{\phi}}\right]_0^\infty$ | M1 A1 | M1 for attempt to deal with the $k=0$ term. A1 for $\frac{\phi}{1-\phi\theta}$ (may be implicit). |
| $= \frac{1}{\phi^k\ k-1\ !} \cdot \frac{\phi^k\ k-1\ !}{(1-\phi\theta)^k} = (1-\phi\theta)^{-k}$ | A1 | Beware printed answer. |
| **[12]** | | |

## Part (ii)

| Answer | Marks | Guidance |
|--------|-------|----------|
| $M_W(\theta) = (1-\phi\theta)^{-nk}$ | B1 | |
| **[1]** | | |

## Part (iii)

| Answer | Marks | Guidance |
|--------|-------|----------|
| $M_Y(\theta) = \left(1 - \frac{2\phi\theta}{\phi}\right)^{-nk} = (1-2\theta)^{-nk}$ | B1 | |
| This is mgf of $\chi^2_{2nk}$, so by inversion theorem/uniqueness property, distribution of $Y$ is $\chi^2_{2nk}$. | M1 B1 | For some allusion to inversion theorem/uniqueness property. May be awarded for correct conclusion even if preceding M1 was not awarded. |
| **[3]** | | |

## Part (iv)

| Answer | Marks | Guidance |
|--------|-------|----------|
| We have $\frac{2W}{\phi} \sim \chi^2_{2nk}$, and $0.95 = P\left(l < \chi^2_{2nk} < u\right)$ | | Must link 0.95, $\chi^2_{2nk}$ to $l$ and $u$, thence to $Y = \frac{2W}{\phi}$. (AG) |
| $\therefore 0.95 = P\left(l < \frac{2W}{\phi} < u\right)$ | | |
| Inserting an observed value $w$ of $W$ gives $2w/u < \phi$ and $2w/l > \phi$ so that a 95% confidence interval for $\phi$ is $(2w/u,\ 2w/l)$. | B2,1,0 | Final CI must not be embedded in a probability statement. |
| **[2]** | | |

## Part (v)

| Answer | Marks | Guidance |
|--------|-------|----------|
| We have $\chi^2_{40}$. | B1 | Follow-through from here if not 40 d.f. |
| Confidence interval is $\left(\frac{2w}{59.34},\ \frac{2w}{24.43}\right)$ | A1 | Both critical points correct, using candidate's d.f. |
| We need $E(W)$. Mgf of $W$ is $M_W(\theta) = (1-\phi\theta)^{-20}$ (see part (ii)). | M1 | For realising $E(W)$ is needed. $nk = 20$ may be seen below. |
| $E(W) = M'(0)$. | M1 | For attempt to find first derivative at zero, or by expanding the series. |
| $M'(\theta) = -20(1-\phi\theta)^{-21}(-\phi)$ $\therefore M'(0) = 20\phi$ | A1 | |
| $\therefore E(\text{length of CI}) = \frac{2 \times 20\phi}{24.43} - \frac{2 \times 20\phi}{59.34}$ | A1 | cao (no follow-through from candidate's incorrect d.f.) |
| $= 40\phi(0.040933 - 0.016852) = 40\phi(0.0240812) = 0.963(25)\phi$ | | Usual penalty for over-specification of final answer. (3 or 4 sf, awrt 0.963) |
| **[6]** | | |
2 (i) The probability density function of the random variable $X$ is

$$\mathrm { f } ( x ) = \frac { x ^ { k - 1 } \mathrm { e } ^ { - x / \phi } } { \phi ^ { k } ( k - 1 ) ! } , x > 0$$

where $k$ is a known positive integer and $\phi$ is an unknown parameter ( $\phi > 0$ ). Show that the moment generating function (mgf) of $X$ is

$$\mathrm { M } _ { X } ( \theta ) = ( 1 - \phi \theta ) ^ { - k }$$

for $\theta < \frac { 1 } { \phi }$.\\
(ii) Write down the mgf of the random variable $W = \sum _ { i = 1 } ^ { n } X _ { i }$ where $X _ { 1 } , X _ { 2 } , \ldots , X _ { n }$ are independent random variables each with the same distribution as $X$.\\
(iii) Write down the mgf of the random variable $Y = \frac { 2 W } { \phi }$. Given that the mgf of the random variable $V$ having the $\chi _ { m } ^ { 2 }$ distribution is $\mathrm { M } _ { V } ( \theta ) = ( 1 - 2 \theta ) ^ { - m / 2 }$ (for $\theta < \frac { 1 } { 2 }$ ), deduce the distribution of $Y$.\\
(iv) Deduce that $\mathrm { P } \left( l < \frac { 2 W } { \phi } < u \right) = 0.95$ where $l$ and $u$ are the lower and upper $2 \frac { 1 } { 2 } \%$ points of the $\chi _ { 2 n k } ^ { 2 }$ distribution. Hence deduce that a $95 \%$ confidence interval for $\phi$ is given by $\left( \frac { 2 w } { u } , \frac { 2 w } { l } \right)$ where $w$ is an observation on the random variable $W$.\\
(v) For the case $k = 2$ and $n = 10$, use percentage points of the $\chi ^ { 2 }$ distribution to write down, in terms of $w$, an expression for a $95 \%$ confidence interval for $\phi$. By considering the $\operatorname { mgf }$ of $W$, find in terms of $\phi$ the expected length of this interval.

\hfill \mbox{\textit{OCR MEI S4 2014 Q2 [24]}}
This paper (2 questions)
View full paper