Abstract
This paper considers the statistical inference for the competing risks model from generalized Rayleigh distribution based on progressive Type-II censoring when the parameters of the latent lifetime distributions are different or common. Maximum likelihood estimates are obtained, where the existence of the point estimators are proved, and the confidence intervals are established via the observed Fisher information matrix as well. Bayesian estimates of unknown parameters and reliability characteristics are derived under symmetric and asymmetric loss functions, and Monte Carlo Markov Chain sampling method is used to compute the Bayesian point estimates and the highest posterior density credible intervals. In addition, Bootstrap methods are also considered to obtain bias-corrected point estimates and approximate confidence intervals. Then we carry out hypothesis test using likelihood ratio test statistics. Monte Carlo simulation and a set of real data are presented to assess the performance of our proposed methods. Finally, the optimal censoring scheme issue is studied.
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Acknowledgements
The authors’ work was partially supported by the National Statistical Science Research Project of China (No. 2019LZ32). The authors would like to thank the editor and anonymous referees for their constructive comments and suggestions that have substantially improved the original manuscript.
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Appendix
Appendix
Proof of Theorem 3.1:
I. For given \(\lambda _k>0\), we have \(0<B_{ki}<1\).
(1) When \(\alpha _k\rightarrow 0^+\), then \(B_{ki}^{\alpha _k}\rightarrow 1^-\) and \(1-B_{ki}^{\alpha _k}\rightarrow 0^+\). \(\sum _{i=1}^mI(\delta _i=k)\log (B_{ki})<0\) is a constant, and we have
therefore, \(\lim \limits _{\alpha _k\rightarrow 0^+}\frac{\partial l}{\partial \alpha _k}=+\infty \).
(2) When \(\alpha _k\rightarrow +\infty \), then \(B_{ki}^{\alpha _k}\rightarrow 0^+\), similarly, \(\sum _{i=1}^mI(\delta _i=k)\log (B_{ki})<0\) is a constant, and we have
therefore, \(\lim \limits _{\alpha _k\rightarrow +\infty }\frac{\partial l}{\partial \alpha _k}\) is a negtive constant.
We can further get
So for given \(\lambda _k\), \(\frac{\partial l}{\partial \alpha _k}\) is a monotone decreasing function of \(\alpha _k\) and the equation \(\frac{\partial l}{\partial \alpha _k}=0\) has an unique solution.
II. For given \(\alpha _k>0\) and \(\alpha _k \ne 1\).
(1) When \(\lambda _k\rightarrow +\infty \), then \(B_{ki}\rightarrow 1^-\) and \(\lim \nolimits _{\lambda _k\rightarrow +\infty }B_{ki}^\prime =2x_i^2 \lim \nolimits _{\lambda _k\rightarrow +\infty } \frac{\lambda _k}{e^{(\lambda _k x_i)^2}}=0^+\),
where \(\lim \nolimits _{\lambda _k\rightarrow +\infty }2\frac{m_k}{\lambda _k}=0\), \(\lim \nolimits _{\lambda _k\rightarrow +\infty }\sum _{i=1}^m(\alpha _k-1)I(\delta _i=k)\frac{B_{ki}^\prime }{B_{ki}}=0\) and
Therefore, \(\lim \limits _{\lambda _k\rightarrow +\infty }-2\lambda _k[\cdot ]=-\infty \) such that \(\lim \limits _{\lambda _k\rightarrow +\infty }\frac{\partial l}{\partial \lambda _k}=-\infty \).
(2) When \(\lambda _k\rightarrow 0^+\), then \(B_{ki}\rightarrow 0^+\) and \(B_{ki}^\prime \rightarrow 0^+\), based on (3.4), we have
For \(\lim \limits _{\lambda _k\rightarrow 0^+}\sum _{i=1}^m(\alpha _k-1)I(\delta _i=k)\frac{B_{ki}^\prime }{B_{ki}}\), we can compute it as follows.
Hence,
We have already known \(B_{ki}^{\alpha _k}\rightarrow 0^+\) and
hence, when \(\alpha _k>1\), \(\lim \limits _{\lambda _k\rightarrow 0^+}-\sum _{i=1}^m(I(\delta _i=3-k)+r_i)\frac{\alpha _kB_{ki}^{\alpha _k-1}B_{ki}^\prime }{1-B_{ki}^{\alpha _k}}=0\), but when \(0<\alpha _k<1\),
And we can get
for arbitrary \(0<\alpha _k<1\), here \(B_{ki}^{\prime \prime }\) is obtained by deriving \(B_{ki}^\prime \) to \(\lambda _k\), namely \(B_{ki}^{\prime \prime }=2x_i^2e^{-(\lambda _k x_i)^2}(1-2x_i^2\lambda _k^2)\). So \(\lim \limits _{\lambda _k\rightarrow 0^+}B_{ki}^{\alpha _k-1}\lambda _k=0\)
We have
According to (A.1), (A.2) and (A.3), for \(\alpha _k>1\), \(\lim \limits _{\lambda _k\rightarrow 0^+}\frac{\partial l}{\partial \lambda _k}=+\infty \). When \(0<\alpha _k<1\), by using L’H\({\hat{o}}\)pital’s rule twice, we have
Therefore, the equation \(\frac{\partial l}{\partial \lambda _k}=0\) has solutions, namely, the MLE of \(\lambda _k\) certainly exists.
Using the inequality \(e^{-t}>1-2t\) for \(t>0\), we have
When \(\alpha _k>1\), it is evident that \(\frac{\partial ^2 l}{\partial \lambda _k^2}<0\) can be derived from (A.4), and MLE of \(\lambda _k\)(\(k=1,2\)) is unique in this case. \(\square \)
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Ren, J., Gui, W. Inference and optimal censoring scheme for progressively Type-II censored competing risks model for generalized Rayleigh distribution. Comput Stat 36, 479–513 (2021). https://doi.org/10.1007/s00180-020-01021-y
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DOI: https://doi.org/10.1007/s00180-020-01021-y