2016
DOI: 10.1080/00031305.2015.1123184
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Confidence Intervals for the Scale Parameter of Exponential Family of Distributions

Abstract: This article presents a unified approach for computing non-equal tail optimal confidence intervals for the scale parameter of the exponential family of distributions. We prove that there exists a pivotal quantity, as a function of a complete sufficient statistic, with a chi-square distribution. Using the similarity between equations of shortest, unbiased and highest density confidence intervals, all equations are reduced into a system of two equations that can be solved via a straightforward algorithm.KEY WORD… Show more

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Cited by 2 publications
(4 citation statements)
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“…The idea, originally proposed by Rufybach et al 3 for tests on the expected value of the normal model, is here extended to the one‐sided testing problem of the scale parameter of exponential families. By exploiting the unifying formulation of Hoshyarmanesh et al, 21 we are able to find expressions of cdf and pdf of the random power of UMP tests that can be specialized to a series of relevant models. Our attention primarily focuses on the choice of the design prior density and on its impact on qualitative features of the resulting distribution of the power.…”
Section: Discussionmentioning
confidence: 99%
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“…The idea, originally proposed by Rufybach et al 3 for tests on the expected value of the normal model, is here extended to the one‐sided testing problem of the scale parameter of exponential families. By exploiting the unifying formulation of Hoshyarmanesh et al, 21 we are able to find expressions of cdf and pdf of the random power of UMP tests that can be specialized to a series of relevant models. Our attention primarily focuses on the choice of the design prior density and on its impact on qualitative features of the resulting distribution of the power.…”
Section: Discussionmentioning
confidence: 99%
“…The joint density function of boldXn$$ {\mathbf{X}}_n $$ is fboldXnfalse(boldxnfalse|θfalse)=hnfalse(boldxnfalse)θmnexp{}prefix−Tfalse(boldxnfalse)θr,$$ {f}_{{\mathbf{X}}_n}\left({\mathbf{x}}_n|\theta \right)=\frac{h_n\left({\mathbf{x}}_n\right)}{\theta^{mn}}\exp \left\{-\frac{T\left({\mathbf{x}}_n\right)}{\theta^r}\right\}, $$ where hnfalse(boldxnfalse)=i=1nhfalse(xifalse)$$ {h}_n\left({\mathbf{x}}_n\right)={\prod}_{i=1}^nh\left({x}_i\right) $$ and where Tfalse(boldxnfalse)=i=1nωfalse(xifalse)$$ T\left({\mathbf{x}}_n\right)={\sum}_{i=1}^n\omega \left({x}_i\right) $$ is a complete sufficient statistic. Following Hoshyarmanesh et al 21 it can be shown that Tfalse(boldXnfalse)Gafalse(ν,θrfalse)$$ T\left({\mathbf{X}}_n\right)\sim \mathrm{Ga}\left(\nu, {\theta}^r\right) $$ where ν=mnfalse/r$$ \nu = mn/r $$ and where in general Gafalse(a,bfalse)$$ \mathrm{Ga}\left(a,b\right) $$ denotes a gamma random variable with shape …”
Section: Methodsmentioning
confidence: 99%
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