Abstract
The recently developed regula-falsi profile likelihood (RF-PL) method has potential for quantifying uncertainty in nonstationary hydrological frequency analysis. However, its applicability to diverse distributions is constrained and lacks comprehensive evaluation. This paper extends the RF-PL method to multiple distributions (Gumbel, Generalized Logistic (GLO), Generalized Normal (GNO), Log-Normal, Log-Pearson type III, and Pearson type III (PE3)) by introducing their reparametrized log-likelihood functions. The extended multi-distribution RF-PL (MD-RF-PL) method is systematically assessed in a simulation study and practical applications, covering diverse nonstationary scenarios, distributions, L-skewness (\({\tau }_{3}\)), and return periods, and compared with the bootstrap and/or the conventional PL as benchmarks. The findings indicate that the MD-RF-PL method is computationally comparable to the bootstrap method but overall superior in capturing the true quantiles with reasonably wide confidence intervals when \({\tau }_{3}\) = 0.1 (moderate tails) and 0.3 (heavy tails). However, when \({\tau }_{3}\) = 0.5 (very heavy tails), although the MD-RF-PL method is superior and roughly equivalent to the bootstrap method for GEV and GLO distributions, respectively, it is inferior for GNO and PE3 distributions, albeit avoiding the occasionally extremely wide confidence intervals of the bootstrap method. This low performance of the MD-RF-PL method is associated with numerical instability. Moreover, the MD-RF-PL method reduces the computational demand of the PL method by 94–99% without degrading its accuracy. Both the simulation study and the practical applications consistently support the preference of the MD-RF-PL method for distributions with moderate to heavy tails and highlight the need for improving its numerical stability for very heavy tails.
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Funding
This work was funded by the Flood Hazard Mapping project of Environment and Climate Change Canada as well as the Canada Research Chair (Tier 1) awarded to Dr. Pietroniro.
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Cuauhtémoc Tonatiuh Vidrio-Sahagún developed the method and wrote the main manuscript text, while Jianxun He and Alain Pietroniro provided supervision of this work and reviewed the manuscript.
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Appendices
Appendix 1: Estimation of confidence interval bounds using the RF-PL method
The RF-PL method considers the target function \(f({y}_{T,{t}_{i}}) ={\mathcal{l}}_{p}\left({y}_{T,{t}_{i}}\right)-{\mathcal{l}}_{p}^{thr}\), where \({y}_{T,{t}_{i}}\) is the effective return level (i.e., the quantile corresponding to a particular \(T\) at time \({t}_{i}\)), \({\mathcal{l}}_{p}\left({y}_{T,{t}_{i}}\right)\) is the profile likelihood of \({y}_{T,{t}_{i}}\), and \({\mathcal{l}}_{p}^{thr}\) is the confidence threshold (see Sect. 2.2). The RF-PL method consists of the following steps:
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1.
Define an initial pair of points denoted by \({y}_{T,{t}_{i}}^{a}\) and \({y}_{T,{t}_{i}}^{b}\) at a given \(T\) and \({t}_{i}\), which enclose a sufficiently large interval such that it contains a zero of \(f({y}_{T,{t}_{i}})\).
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2.
Calculate the approximated zero as \({y}_{T,{t}_{i}}^{c}=\frac{{y}_{T,{t}_{i}}^{b}f\left({y}_{T,{t}_{i}}^{a}\right)-{y}_{T,{t}_{i}}^{a}f\left({y}_{T,{t}_{i}}^{b}\right)}{f\left({y}_{T,{t}_{i}}^{a}\right)-f\left({y}_{T,{t}_{i}}^{b}\right)}\).
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3.
Re-define the interval as \([{y}_{T,{t}_{i}}^{a},{y}_{T,{t}_{i}}^{c}]\) if \(f\left({y}_{T,{t}_{i}}^{a}\right)f\left({y}_{T,{t}_{i}}^{c}\right)<0\) or as \([{y}_{T,{t}_{i}}^{c}, {y}_{T,{t}_{i}}^{b}]\) if \(f\left({y}_{T,{t}_{i}}^{c}\right)f\left({y}_{T,{t}_{i}}^{b}\right)<0\), such that the interval keeps containing the zero.
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4.
Stop the iteration if the error \(f\left({y}_{T,{t}_{i}}^{c}\right)\) is less than or equal to the pre-defined error tolerance \(\varepsilon\); otherwise, repeat steps 2 and 3 until the error is less than or equal to \(\varepsilon\).
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5.
Repeat steps 1 to 4 for all the \(T\) s and \({t}_{i}\) s of interest.
The \(\varepsilon =\left|0.01\left[\mathcal{l}\left(\widehat{{\varvec{\theta}}}\right)-{\mathcal{l}}_{p}^{thr}\left({\theta }_{j}\right)\right]\right|\) was adopted after verifying it was adequate for the target problem after scrutiny (Vidrio-Sahagún and He 2022a). The \(\widehat{{\varvec{\theta}}}\) is obtained by maximizing \({\mathcal{l}}_{p}\left({\theta }_{j}\right)\) as in the maximum likelihood estimation method.
Appendix 2: Candidate distributions
See Table 3.
Appendix 3: Nonstationary generic log-likelihood functions
See Table 4.
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Vidrio-Sahagún, C.T., He, J. & Pietroniro, A. Multi-distribution regula-falsi profile likelihood method for nonstationary hydrological frequency analysis. Stoch Environ Res Risk Assess 38, 843–867 (2024). https://doi.org/10.1007/s00477-023-02603-0
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DOI: https://doi.org/10.1007/s00477-023-02603-0