Abstract
In this paper, we discuss the existence and uniqueness of the maximum likelihood estimates (MLEs) of the parameters of Laplace Birnbaum–Saunders distribution based on Type-I, Type-II and hybrid censored samples. We first derive the relationship between the MLEs of the two parameters and then discuss the monotonicity property of the profile likelihood function. Numerical iterative procedure is then discussed for determining the MLEs of the parameters. Finally, for illustrative purpose, we analyze one real data from the literature and present some graphical illustrations of the approach.
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Acknowledgements
We express our sincere thanks to the anonymous reviewers for their useful comments and suggestion on an earlier version of this manuscript which led to this improved version.
Funding
This research was supported by the National Natural Science Foundation of China—Young Scientists Fund [No. 11801459], Jiangsu Science and Technology Programme—The Young-Scholar Programme [No. BK20180241] and the Research Development Fund of Xian-Jiaotong Liverpool University [No. RDF-17-01-20]. The second author thanks the Natural Sciences and Engineering Research Council of Canada for supporting this research.
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Appendix
Appendix
Proof of Remark 1
It is clear that \(\alpha (\beta ,t_{k:n},k)\) in (12), for \(\beta \le t_{k:n}\), is not differentiable at \(\beta =t_{i:n}\), for \(i=1,\ldots ,k\). However, it is continuous, and so we can consider \(\alpha (\beta ,t_{k:n},k)\) reaches the local maximum or local minimum at t if \(\lim \nolimits _{x\rightarrow t^+} \alpha '(x,t_{k:n},k)\lim \nolimits _{x\rightarrow t^-}\alpha '(x,t_{k:n},k)<0\). For the sake of convenience, we define \(\alpha '(x,t_{k:n},k)=0\) if \(\lim \nolimits _{x\rightarrow t^+} \alpha '(x,t_{k:n},k)\lim \nolimits _{x\rightarrow t^-}\alpha '(x,t_{k:n},k)<0\). Now, if \(t_{j:n}<\beta <t_{j+1:n}\), \(j=0,\ldots ,k-1,\) with \(t_{0:n}\equiv 0\), then the first derivative of \(\alpha \) with respect to \(\beta \) is given by
It is clear that when \(\beta \rightarrow 0\), we have \(j=0\) and so
We also have
and
which suggests that there exists at most one root for \([\beta \alpha '(\beta ,t_{k:n},k)]=0\), thus showing that there exists at most one root for \(\alpha '(\beta ,t_{k:n},k)=0\) in turn. We can thus conclude the lemma, as required. \(\square \)
Proof of Lemma 1
Let us consider the first derivative of \(\ln L_{profile}\) with respect to \(\beta \) in each interval \((t_{j:n} , t_{j+1:n})\), for \(j=0,\ldots , k-1\), with \(t_0\equiv 0\), given by
where \(\gamma (\beta )=-\beta ^2 k\alpha '(\beta ,t_{k:n},k)+\beta \alpha (\beta ,t_{k:n},k)\sum \nolimits _{i=1}^k\frac{\beta -t_{i:n}}{2(\beta +t_{i:n})}\).
Moreover, we have
Thus, if \(\lim _{\beta \rightarrow t_{k:n}^-}\ln L'_{pro}<0\), then there must exist a \(\beta _0\) such that \(\gamma (\beta )>0\) for \(\beta <\beta _0\) and \(\gamma (\beta )<0\) for \(\beta >\beta _0\). We show in the following once \(\gamma (\beta )<0\), then \(\gamma (\beta )\) will be a decreasing function of \(\beta \), which in turn suggests that there will be no root for \(\gamma (\beta )=0\) for \(\beta >\beta _0\). The first derivative of \(\gamma (\beta )\) is
Moreover, for any non-differentiable point \(t_{j:n}\) for \(j=1,\ldots ,k-1\), we have
We can thus conclude that if \(\lim \nolimits _{\beta \rightarrow t_{k:n}}\ln L'_{pro}<0\), then there exists only one root for the equation \(\ln L'_{pro}(\beta )=0\) for \(\beta \le t_{k:n}\), and if \(\lim \nolimits _{\beta \rightarrow t_{k:n}}\ln L'_{pro}>0\), then there will be no root for the equation \(\ln L'_{pro}(\beta )=0\) for \(\beta \le t_{k:n}\). \(\square \)
Proof of Lemma 3
We will first prove that \(H(\eta (\beta ,t_{k:n}))\) is a decreasing function of \(\beta \) for \(\beta >t_{k:n}\). It is well-known that the hazard function of the standard Laplace distribution is an increasing function of x for \(x<0\) and a constant for \(x\ge 0\). Studying the monotonicity of \(H(\eta (\beta ,t_{k:n}))\) is equivalent to studying the property of \(\eta (\beta ,t_{k:n})\), where
Let us denote \(g_1(\beta )=\left( \sqrt{\frac{\beta ^2}{t_{k:n}}}-\sqrt{t_{k:n}}\right) \left( {\sum \limits _{i=1}^k\frac{t_{k:n}+t_{i:n}}{t_{i:n}+\beta }}\right) \); we then have
Hence, \(\eta (\beta ,t_{k:n})\) is a decreasing function of \(\beta \).
Next, we will prove that \(\alpha (\beta ,t_{k:n},k)\sqrt{\beta }\sum \nolimits _{i=1}^k\frac{t_{i:n}}{t_{i:n}+\beta }=g_2(\beta )\) is an increasing function of \(\beta \) for \(\beta >t_{k:n}\), where
Let us consider
then, we have
showing the monotonicity of \(g_2(\beta )\) and then \(G(\beta )\) in turn.
Moreover, we have
\(\square \)
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Zhu, X., Balakrishnan, N. & Saulo, H. On the existence and uniqueness of the maximum likelihood estimates of parameters of Laplace Birnbaum–Saunders distribution based on Type-I, Type-II and hybrid censored samples. Metrika 82, 759–778 (2019). https://doi.org/10.1007/s00184-019-00707-8
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DOI: https://doi.org/10.1007/s00184-019-00707-8
Keywords
- Birnbaum–Saunders distribution
- Existence
- Generalized Birnbaum–Saunders distribution
- Hybrid censoring
- Laplace Birnbaum–Saunders distribution
- Maximum likelihood estimate
- Type-I censoring
- Type-II censoring
- Uniqueness