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Search Results (634)

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19 pages, 4885 KiB  
Article
Data-Driven State of Health Interval Prediction for Lithium-Ion Batteries
by Ziyao Song, Han Zhang and Jianfang Jia
Electronics 2024, 13(20), 3991; https://doi.org/10.3390/electronics13203991 - 11 Oct 2024
Viewed by 464
Abstract
The accurate prediction of the state of health (SOH) for lithium-ion batteries is a key factor for improving the performance of battery management systems (BMS). However, traditional point prediction methods are difficult to effectively eliminate errors due to the uncertainty of variables and [...] Read more.
The accurate prediction of the state of health (SOH) for lithium-ion batteries is a key factor for improving the performance of battery management systems (BMS). However, traditional point prediction methods are difficult to effectively eliminate errors due to the uncertainty of variables and application environments. This paper presents a model for predicting the interval of lithium-ion batteries based on health indicators (HIs) during charging, which addresses the limitations of current point prediction in practical applications. First, twelve HIs are extracted from the current and voltage variables of the charging process. Secondly, feature selection is performed by random forest (RF) training, and the selected HIs are dimensioned using partial least squares (PLS). Finally, a long short-term memory network (LSTM) combined with quantile regression (QR) is used to derive the quantile values of the prediction points and each quantile is employed as input information for Gaussian kernel density estimation (KDE) to obtain the SOH probability density distribution. The experimental results based on the NASA PCOE Li-ion battery dataset and CALCE Li-ion battery dataset show that the SOH interval coverage is more than 90% and the average width of the interval is less than 0.294. Full article
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Figure 1

Figure 1
<p>Charging process curve: (<b>a</b>) charging voltage and current curves; (<b>b</b>) charge IC curve.</p>
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<p>RF training feature results. (<b>a</b>) The importance results. (<b>b</b>) Training error results.</p>
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<p>Results of principal component contribution after dimensionality reduction in PLS features.</p>
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<p>A structure diagram of the LSTM model.</p>
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<p>The validation framework of the proposed SOH estimation model.</p>
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<p>#5 predicted results: (<b>a</b>) number of training is 50%; (<b>b</b>) number of training is 60%; (<b>c</b>) number of training is 70%.</p>
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<p>#6 predicted results: (<b>a</b>) number of training is 50%; (<b>b</b>) number of training is 60%; (<b>c</b>) number of training is 70%.</p>
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<p>#7 predicted results: (<b>a</b>) number of training is 50%; (<b>b</b>) number of training is 60%; (<b>c</b>) number of training is 70%.</p>
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<p>#18 predicted results: (<b>a</b>) number of training is 50%; (<b>b</b>) number of training is 60%; (<b>c</b>) number of training is 70%.</p>
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<p>#5 results of kernel density estimation for 50% of training data: (<b>a</b>) 1st quartile; (<b>b</b>) 30th quartile; (<b>c</b>) 50th quartile; (<b>d</b>) 70th quartile; (<b>e</b>) 76th quartile; (<b>f</b>) 84th quartile.</p>
Full article ">Figure 11
<p>#5 results of kernel density estimation for 60% of training data: (<b>a</b>) 1st quartile; (<b>b</b>) 30th quartile; (<b>c</b>) 50th quartile; (<b>d</b>) 55th quartile; (<b>e</b>) 60th quartile; (<b>f</b>) 67th quartile.</p>
Full article ">Figure 11 Cont.
<p>#5 results of kernel density estimation for 60% of training data: (<b>a</b>) 1st quartile; (<b>b</b>) 30th quartile; (<b>c</b>) 50th quartile; (<b>d</b>) 55th quartile; (<b>e</b>) 60th quartile; (<b>f</b>) 67th quartile.</p>
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<p>#5 results of kernel density estimation for 70% of training data: (<b>a</b>) 2nd quartile A; (<b>b</b>) 13th quartile; (<b>c</b>) 23rd quartile; (<b>d</b>) 33rd quartile; (<b>e</b>) 43rd quartile; (<b>f</b>) 50th quartile.</p>
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<p>#CS2_35 predicted results: (<b>a</b>) number of training is 50%; (<b>b</b>) number of training is 60%; (<b>c</b>) number of training is 70%.</p>
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<p>#CS2_36 predicted results: (<b>a</b>) number of training is 50%; (<b>b</b>) number of training is 60%; (<b>c</b>) number of training is 70%.</p>
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<p>#CS2_37 predicted results: (<b>a</b>) number of training is 50%; (<b>b</b>) number of training is 60%; (<b>c</b>) number of training is 70%.</p>
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<p>#CS2_38 predicted results: (<b>a</b>) number of training is 50%; (<b>b</b>) number of training is 60%; (<b>c</b>) number of training is 70%.</p>
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<p>CS2_35 results of kernel density estimation for 50% of training data: (<b>a</b>) 1st quartile; (<b>b</b>) 20th quartile; (<b>c</b>) 40th quartile; (<b>d</b>) 55th quartile; (<b>e</b>) 70th quartile; (<b>f</b>) 80th quartile.</p>
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<p>CS2_35 results of kernel density estimation for 60% of training data: (<b>a</b>) 1st quartile; (<b>b</b>) 20th quartile; (<b>c</b>) 40th quartile; (<b>d</b>) 55th quartile; (<b>e</b>) 70th quartile; (<b>f</b>) 80th quartile.</p>
Full article ">Figure 19
<p>CS2_35 results of kernel density estimation for 70% of training data: (<b>a</b>) 1st quartile; (<b>b</b>) 20th quartile; (<b>c</b>) 40th quartile; (<b>d</b>) 55th quartile; (<b>e</b>) 70th quartile; (<b>f</b>) 80th quartile.</p>
Full article ">Figure 19 Cont.
<p>CS2_35 results of kernel density estimation for 70% of training data: (<b>a</b>) 1st quartile; (<b>b</b>) 20th quartile; (<b>c</b>) 40th quartile; (<b>d</b>) 55th quartile; (<b>e</b>) 70th quartile; (<b>f</b>) 80th quartile.</p>
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10 pages, 1051 KiB  
Article
Associations between Dietary Patterns, Fluoride Intake and Excretion in Women Exposed to Fluoridated Salt: A Preliminary Study
by Gina A. Castiblanco-Rubio, Michele Baston, Mauricio Hernandez-F, E. Angeles Martinez-Mier and Alejandra Cantoral
Nutrients 2024, 16(19), 3404; https://doi.org/10.3390/nu16193404 - 8 Oct 2024
Viewed by 446
Abstract
Abundant information exists on fluoride intake and excretion in populations exposed to fluoridated water, but not fluoridated salt, where fluoride is eaten through a combination of foods and beverages. This study assessed associations between dietary patterns, fluoride intake and excretion in Mexican women [...] Read more.
Abundant information exists on fluoride intake and excretion in populations exposed to fluoridated water, but not fluoridated salt, where fluoride is eaten through a combination of foods and beverages. This study assessed associations between dietary patterns, fluoride intake and excretion in Mexican women exposed to fluoridated salt. We estimated dietary fluoride intake and excretion (mg/day) from 31 women using 24-h recalls (ASA24) and 24-h urine collections (HDMS diffusion method) and assessed agreement among both estimates of exposure with a Bland-Altman plot. Dietary patterns among the sample were explored by Principal Component Analysis and associations between these patterns and both fluoride intake and excretion were estimated. using Quantile Regressions. Median dietary fluoride intake and excretion were 0.95 and 0.90 mg/day, respectively, with better agreement at values below 1.5 mg/day. We identified three dietary patterns: “Urban Convenience”, “Plant-based” and “Egg-based”. The “Urban Convenience” pattern, characterized by dairy and convenience foods was associated with an increase of 0.25 mg and 0.34 mg of F in the 25th and 50th percentiles of intake respectively, (p < 0.01), and a marginal 0.22 mg decrease in urinary fluoride (p = 0.06). In conclusion, in this sample of Mexican women, a dietary pattern rich in dairy and convenience foods, was associated with both fluoride intake and excretion. Full article
(This article belongs to the Special Issue Dietary Fluoride Intake, Metabolism and Health)
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Figure 1
<p>Flow chart of study recruitment strategy and final sample.</p>
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<p>Agreement between estimates of dietary fluoride intake (ASA24 dietary recall) and 24-h urinary fluoride levels.</p>
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<p>Effect of dietary patterns on the 50th percentile of dietary fluoride intake (95% Confidence Intervals: (<b>a</b>) Dietary Fluoride Intake; (<b>b</b>) Urinary Fluoride Excretion.</p>
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16 pages, 297 KiB  
Article
Empirical Likelihood for Composite Quantile Regression Models with Missing Response Data
by Shuanghua Luo, Yu Zheng and Cheng-yi Zhang
Symmetry 2024, 16(10), 1314; https://doi.org/10.3390/sym16101314 - 5 Oct 2024
Viewed by 580
Abstract
Under the assumption of missing response data, empirical likelihood inference is studied via composite quantile regression. Firstly, three empirical likelihood ratios of composite quantile regression are given and proved to be asymptotically χ2. Secondly, without an estimation of the asymptotic covariance, [...] Read more.
Under the assumption of missing response data, empirical likelihood inference is studied via composite quantile regression. Firstly, three empirical likelihood ratios of composite quantile regression are given and proved to be asymptotically χ2. Secondly, without an estimation of the asymptotic covariance, confidence intervals are constructed for the regression coefficients. Thirdly, three estimators are presented for the regression parameters to obtain its asymptotic distribution. The finite sample performance is assessed through simulation studies, and the symmetry confidence intervals of the parametric are constructed. Finally, the effectiveness of the proposed methods is illustrated by analyzing a real-world data set. Full article
9 pages, 2217 KiB  
Article
Changes in Central Sensitivity to Thyroid Hormones vs. Urine Iodine during Pregnancy
by Ioannis Ilias, Charalampos Milionis, Maria Alexiou, Ekaterini Michou, Chrysi Karavasili, Evangelia Venaki, Kostas Markou, Irini Mamali and Eftychia Koukkou
Med. Sci. 2024, 12(4), 50; https://doi.org/10.3390/medsci12040050 - 27 Sep 2024
Viewed by 399
Abstract
Introduction/Aim: Central sensitivity to thyroid hormones refers to the responsiveness of the hypothalamic–pituitary–thyroid (HPT) axis to changes in circulating free thyroxine (fT4). Although dose–response relationships between thyroid hormones per se and urinary iodine (UI) levels have been observed, central sensitivity to thyroid hormones [...] Read more.
Introduction/Aim: Central sensitivity to thyroid hormones refers to the responsiveness of the hypothalamic–pituitary–thyroid (HPT) axis to changes in circulating free thyroxine (fT4). Although dose–response relationships between thyroid hormones per se and urinary iodine (UI) levels have been observed, central sensitivity to thyroid hormones in relation to UI remains unexplored. The aim of the present study was to evaluate central sensitivity to thyroid hormones (by means of the Thyroid Feedback Quantile-based Index [TFQI], which is a calculated measure, based on TSH and fT4, that estimates central sensitivity to thyroid hormones) in pregnancy and to assess whether it differs according to gestational age and/or iodine intake. Materials and Methods: One thousand, one hundred and two blood and urine samples were collected from pregnant women (with a mean age ± SD of 30.4 ± 4.6 years) during singleton pregnancies; women with known/diagnosed thyroid disease were excluded. Specifically, TSH and fT4, anti-thyroid peroxidase antibodies and UI were measured in each trimester and at two months postpartum, while the TFQI was calculated for all the study samples. After the elimination of outliers, statistical analysis was conducted with analysis of variance (ANOVA) for the variables versus time period, while Pearson’s correlation was used to assess the TFQI versus UI. Results: The mean TFQI index ranged from −0.060 (second trimester) to −0.053 (two months postpartum), while the corresponding UI was 137 and 165 μg/L, respectively. The TFQI-UI correlation was marginally negative (Pearson r: −0.323, p: 0.04) and significantly positive (r: +0.368, p: 0.050) for UI values over 250 μg/L, in the first and the second trimesters of pregnancy, respectively. Discussion: The TFQI is a new index reflecting central sensitivity to thyroid hormones. A lower TFQI indicates higher sensitivity to thyroid hormones. In our sample, the TFQI was mainly positively related to iodine intake in the second trimester of pregnancy (following the critical period of organogenesis). Thus, the observed changes in the TFQI may reflect the different ways of the central action of thyroid hormones, according to the phase of pregnancy. These results have the potential to enhance our comprehension of the changes in the HPT axis’ function via variations in central sensitivity to thyroid hormones and its interplay with nutritional iodine status during pregnancy. Full article
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Figure 1

Figure 1
<p>A flow chart of the study; TFT: thyroid function tests (and anti-thyroid peroxidase antibodies); UI: urine iodine; TFQI: Thyroid Feedback Quantile-based Index; Q1: first quartile; Q3: third quartile; IQR: inter-quartile range.</p>
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<p>Scatter plots with ordinary least squares (OLS) regression lines for the TFQI vs. urine iodine (UI) levels up to 250 μg/L (<b>A</b>) and above 250 μg/L (<b>B</b>) during each trimester and the postpartum period (PP). Note: In the postpartum period, only one UI measurement exceeded 250 μg/L, precluding OLS regression for this time period.</p>
Full article ">Figure 2 Cont.
<p>Scatter plots with ordinary least squares (OLS) regression lines for the TFQI vs. urine iodine (UI) levels up to 250 μg/L (<b>A</b>) and above 250 μg/L (<b>B</b>) during each trimester and the postpartum period (PP). Note: In the postpartum period, only one UI measurement exceeded 250 μg/L, precluding OLS regression for this time period.</p>
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20 pages, 540 KiB  
Article
Inverse Probability-Weighted Estimation for Dynamic Structural Equation Model with Missing Data
by Hao Cheng
Mathematics 2024, 12(19), 3010; https://doi.org/10.3390/math12193010 - 26 Sep 2024
Viewed by 380
Abstract
In various applications, observed variables are missing some information that was intended to be collected. The estimations of both loading and path coefficients could be biased when ignoring the missing data. Inverse probability weighting (IPW) is one of the well-known methods helping to [...] Read more.
In various applications, observed variables are missing some information that was intended to be collected. The estimations of both loading and path coefficients could be biased when ignoring the missing data. Inverse probability weighting (IPW) is one of the well-known methods helping to reduce bias in regressions, while belonging to a promising but new category in structural equation models. The paper proposes both parametric and nonparametric IPW estimation methods for dynamic structural equation models, in which both loading and path coefficients are developed into functions of a random variable and of the quantile level. To improve the computational efficiency, modified parametric IPW and modified nonparametric IPW are developed through reducing inverse probability computations but making fuller use of completely observed information. All the above IPW estimation methods are compared to existing complete case analysis through simulation investigations. Finally, the paper illustrates the proposed model and estimation methods by an empirical study on digital new-quality productivity. Full article
(This article belongs to the Section Computational and Applied Mathematics)
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Figure 1
<p>Dynamic structural equation model with missing data. The observed variable <math display="inline"><semantics> <msub> <mi mathvariant="script">X</mi> <mn>1</mn> </msub> </semantics></math> contains missing data, and all the other observed variables <math display="inline"><semantics> <msub> <mi mathvariant="script">Y</mi> <mn>11</mn> </msub> </semantics></math>, <math display="inline"><semantics> <msub> <mi mathvariant="script">Y</mi> <mn>12</mn> </msub> </semantics></math>, <math display="inline"><semantics> <msub> <mi mathvariant="script">Y</mi> <mn>21</mn> </msub> </semantics></math>, <math display="inline"><semantics> <msub> <mi mathvariant="script">Y</mi> <mn>22</mn> </msub> </semantics></math>, <math display="inline"><semantics> <msub> <mi mathvariant="script">X</mi> <mn>2</mn> </msub> </semantics></math> are completely observed.</p>
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<p>Missing data distribution under <b>S1</b> and <b>S2</b> with sample size of 500.</p>
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17 pages, 3707 KiB  
Article
Extreme Value Index Estimation for Pareto-Type Tails under Random Censorship and via Generalized Means
by M. Ivette Gomes, Lígia Henriques-Rodrigues, M. Manuela Neves and Helena Penalva
Appl. Sci. 2024, 14(19), 8671; https://doi.org/10.3390/app14198671 - 26 Sep 2024
Viewed by 390
Abstract
The field of statistical extreme value theory (EVT) focuses on estimating parameters associated with extreme events, such as the probability of exceeding a high threshold or determining a high quantile that lies at or beyond the observed data range. Typically, the assumption for [...] Read more.
The field of statistical extreme value theory (EVT) focuses on estimating parameters associated with extreme events, such as the probability of exceeding a high threshold or determining a high quantile that lies at or beyond the observed data range. Typically, the assumption for univariate data analysis is that the sample is complete, independent, identically distributed, or weakly dependent and stationary, drawn from an unknown distribution F. However, in the context of lifetime data, censoring is a common issue. In this work, we consider the case of random censoring for data with a heavy-tailed, Pareto-type distribution. As is common in applications of EVT, the estimation of the extreme value index (EVI) is critical, as it quantifies the tail heaviness of the distribution. The EVI has been extensively studied in the literature. Here, we discuss several classical EVI-estimators and reduced-bias (RB) EVI-estimators within a semi-parametric framework, with a focus on RB EVI-estimators derived from generalized means, which will be applied to both simulated and real survival data. Full article
(This article belongs to the Special Issue Applied Biostatistics: Challenges and Opportunities)
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Figure 1

Figure 1
<p>Sample paths of <math display="inline"><semantics> <mrow> <msub> <mover accent="true"> <mi>ξ</mi> <mo>^</mo> </mover> <mi>X</mi> </msub> <mrow> <mo>(</mo> <mi>k</mi> <mo>)</mo> </mrow> </mrow> </semantics></math> (<b>on the left</b>) and of <math display="inline"><semantics> <mrow> <msub> <mover accent="true"> <mi>ξ</mi> <mo>^</mo> </mover> <mi>Z</mi> </msub> <mrow> <mo>(</mo> <mi>k</mi> <mo>)</mo> </mrow> </mrow> </semantics></math> (<b>on the right</b>) for samples of size 1000 from the Fréchet parents under study.</p>
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<p>RMSEs of <math display="inline"><semantics> <mrow> <msub> <mover accent="true"> <mi>ξ</mi> <mo>^</mo> </mover> <mi>X</mi> </msub> <mrow> <mo>(</mo> <mi>k</mi> <mo>)</mo> </mrow> </mrow> </semantics></math> (<b>on the left</b>) and of <math display="inline"><semantics> <mrow> <msub> <mover accent="true"> <mi>ξ</mi> <mo>^</mo> </mover> <mi>Z</mi> </msub> <mrow> <mo>(</mo> <mi>k</mi> <mo>)</mo> </mrow> </mrow> </semantics></math> (<b>on the right</b>) for samples of size 1000 from the Fréchet parents under study.</p>
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<p>Sample paths of <math display="inline"><semantics> <mrow> <msub> <mover accent="true"> <mi>ξ</mi> <mo>^</mo> </mover> <mi>X</mi> </msub> <mrow> <mo>(</mo> <mi>k</mi> <mo>)</mo> </mrow> </mrow> </semantics></math> (<b>on the left</b>) and of <math display="inline"><semantics> <mrow> <msub> <mover accent="true"> <mi>ξ</mi> <mo>^</mo> </mover> <mi>Z</mi> </msub> <mrow> <mo>(</mo> <mi>k</mi> <mo>)</mo> </mrow> </mrow> </semantics></math> (<b>on the right</b>) for samples of size 100 from the Fréchet parents under study.</p>
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<p>RMSEs of <math display="inline"><semantics> <mrow> <msub> <mover accent="true"> <mi>ξ</mi> <mo>^</mo> </mover> <mi>X</mi> </msub> <mrow> <mo>(</mo> <mi>k</mi> <mo>)</mo> </mrow> </mrow> </semantics></math> (<b>on the left</b>) and of <math display="inline"><semantics> <mrow> <msub> <mover accent="true"> <mi>ξ</mi> <mo>^</mo> </mover> <mi>Z</mi> </msub> <mrow> <mo>(</mo> <mi>k</mi> <mo>)</mo> </mrow> </mrow> </semantics></math> (<b>on the right</b>) for samples of size 100 from the Fréchet parents under study.</p>
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<p>Sample paths of <math display="inline"><semantics> <msub> <mover accent="true"> <mi>c</mi> <mo>^</mo> </mover> <mrow> <mi>k</mi> <mo>,</mo> <mi>n</mi> </mrow> </msub> </semantics></math> based on 1000 replicates of samples of size 100 (<b>on the left</b>) and samples of size 1000 (<b>on the right</b>) from the Fréchet parents under study.</p>
Full article ">Figure 6
<p>Sample paths of <math display="inline"><semantics> <mrow> <msub> <mover accent="true"> <mi>ξ</mi> <mo>^</mo> </mover> <mi>X</mi> </msub> <mrow> <mo>(</mo> <mi>k</mi> <mo>)</mo> </mrow> </mrow> </semantics></math> (<b>on the left</b>) and of <math display="inline"><semantics> <mrow> <msub> <mover accent="true"> <mi>ξ</mi> <mo>^</mo> </mover> <mi>Z</mi> </msub> <mrow> <mo>(</mo> <mi>k</mi> <mo>)</mo> </mrow> </mrow> </semantics></math> (<b>on the right</b>) for samples of size 1000 from the Burr<math display="inline"><semantics> <mrow> <mo>(</mo> <mi>ξ</mi> <mo>,</mo> <mi>ρ</mi> <mo>=</mo> <mo>−</mo> <mn>1</mn> <mo>)</mo> </mrow> </semantics></math> parents under study.</p>
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<p>RMSEs of <math display="inline"><semantics> <mrow> <msub> <mover accent="true"> <mi>ξ</mi> <mo>^</mo> </mover> <mi>X</mi> </msub> <mrow> <mo>(</mo> <mi>k</mi> <mo>)</mo> </mrow> </mrow> </semantics></math> (<b>on the left</b>) and of <math display="inline"><semantics> <mrow> <msub> <mover accent="true"> <mi>ξ</mi> <mo>^</mo> </mover> <mi>Z</mi> </msub> <mrow> <mo>(</mo> <mi>k</mi> <mo>)</mo> </mrow> </mrow> </semantics></math> (<b>on the right</b>) for samples of size 1000 from the Burr<math display="inline"><semantics> <mrow> <mo>(</mo> <mi>ξ</mi> <mo>,</mo> <mi>ρ</mi> <mo>=</mo> <mo>−</mo> <mn>1</mn> <mo>)</mo> </mrow> </semantics></math> parents under study.</p>
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<p>Sample paths of <math display="inline"><semantics> <msub> <mover accent="true"> <mi>c</mi> <mo>^</mo> </mover> <mrow> <mi>k</mi> <mo>,</mo> <mi>n</mi> </mrow> </msub> </semantics></math> based on 1000 replicates of samples of size 1000 from the Burr parents under study.</p>
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<p>Sample paths of <math display="inline"><semantics> <mrow> <msub> <mover accent="true"> <mi>ξ</mi> <mo>^</mo> </mover> <mi>X</mi> </msub> <mrow> <mo>(</mo> <mi>k</mi> <mo>)</mo> </mrow> </mrow> </semantics></math> (<b>on the left</b>) and of <math display="inline"><semantics> <mrow> <msub> <mover accent="true"> <mi>ξ</mi> <mo>^</mo> </mover> <mi>Z</mi> </msub> <mrow> <mo>(</mo> <mi>k</mi> <mo>)</mo> </mrow> </mrow> </semantics></math> (<b>on the right</b>) for samples of size 1000 from the GP<math display="inline"><semantics> <mrow> <mo>(</mo> <mi>ξ</mi> <mo>)</mo> </mrow> </semantics></math> parents under study.</p>
Full article ">Figure 10
<p>RMSE of <math display="inline"><semantics> <mrow> <msub> <mover accent="true"> <mi>ξ</mi> <mo>^</mo> </mover> <mi>X</mi> </msub> <mrow> <mo>(</mo> <mi>k</mi> <mo>)</mo> </mrow> </mrow> </semantics></math> (<b>on the left</b>) and of <math display="inline"><semantics> <mrow> <msub> <mover accent="true"> <mi>ξ</mi> <mo>^</mo> </mover> <mi>Z</mi> </msub> <mrow> <mo>(</mo> <mi>k</mi> <mo>)</mo> </mrow> </mrow> </semantics></math> (<b>on the right</b>) for samples of size 1000 from the GP<math display="inline"><semantics> <mrow> <mo>(</mo> <mi>ξ</mi> <mo>)</mo> </mrow> </semantics></math> parents under study.</p>
Full article ">Figure 11
<p>Sample paths of <math display="inline"><semantics> <msub> <mover accent="true"> <mi>c</mi> <mo>^</mo> </mover> <mrow> <mi>k</mi> <mo>,</mo> <mi>n</mi> </mrow> </msub> </semantics></math> based on 1000 replicates of samples of 1000 from the GP parents under study.</p>
Full article ">Figure 12
<p>Sample path of <math display="inline"><semantics> <msub> <mover accent="true"> <mi>c</mi> <mo>^</mo> </mover> <mrow> <mi>k</mi> <mo>,</mo> <mi>n</mi> </mrow> </msub> </semantics></math> and adaptive estimate <math display="inline"><semantics> <mover accent="true"> <mi>c</mi> <mo>˜</mo> </mover> </semantics></math> for the tongue cancer data.</p>
Full article ">Figure 13
<p>Sample paths of <math display="inline"><semantics> <mrow> <msub> <mover accent="true"> <mi>ξ</mi> <mo>^</mo> </mover> <mi>X</mi> </msub> <mrow> <mo>(</mo> <mi>k</mi> <mo>)</mo> </mrow> </mrow> </semantics></math> (<b>on the left</b>) and of <math display="inline"><semantics> <mrow> <msub> <mover accent="true"> <mi>ξ</mi> <mo>^</mo> </mover> <mi>Z</mi> </msub> <mrow> <mo>(</mo> <mi>k</mi> <mo>)</mo> </mrow> </mrow> </semantics></math> (<b>on the right</b>) for the tongue cancer data.</p>
Full article ">
30 pages, 3076 KiB  
Article
Constant Stress-Partially Accelerated Life Tests of Vtub-Shaped Lifetime Distribution under Progressive Type II Censoring
by Aisha Fayomi, Asmaa A. Ahmed, Neama T. AL-Sayed, Sara M. Behairy, Asmaa M. Abd AL-Fattah, Gannat R. AL-Dayian and Abeer A. EL-Helbawy
Symmetry 2024, 16(9), 1251; https://doi.org/10.3390/sym16091251 - 23 Sep 2024
Viewed by 471
Abstract
In lifetime tests, the waiting time for items to fail may be long under usual use conditions, particularly when the products have high reliability. To reduce the cost of testing without sacrificing the quality of the data obtained, the products are exposed to [...] Read more.
In lifetime tests, the waiting time for items to fail may be long under usual use conditions, particularly when the products have high reliability. To reduce the cost of testing without sacrificing the quality of the data obtained, the products are exposed to higher stress levels than normal, which quickly causes early failures. Therefore, accelerated life testing is essential since it saves costs and time. This paper considers constant stress-partially accelerated life tests under progressive Type II censored samples. This is realized under the claim that the lifetime of products under usual use conditions follows Vtub-shaped lifetime distribution, which is also known as log-log distribution. The log–log distribution is highly significant and has several real-world applications since it has distinct shapes of its probability density function and hazard rate function. A graphical description of the log–log distribution is exhibited, including plots of the probability density function and hazard rate. The log–log density has different shapes, such as decreasing, unimodal, and approximately symmetric. Several mathematical properties, such as quantiles, probability weighted moments, incomplete moments, moments of residual life, and reversed residual life functions, and entropy of the log–log distribution, are discussed. In addition, the maximum likelihood and maximum product spacing methods are used to obtain the interval and point estimators of the acceleration factor, as well as the model parameters. A simulation study is employed to assess the implementation of the estimation approaches under censoring schemes and different sample sizes. Finally, to demonstrate the viability of the various approaches, two real data sets are investigated. Full article
(This article belongs to the Section Mathematics)
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<p>Plots of the pdf and hrf of the LL distribution for various values of the parameters <inline-formula><mml:math id="mm427"><mml:semantics><mml:mrow><mml:mi mathvariant="bold-italic">α</mml:mi><mml:mo> </mml:mo></mml:mrow></mml:semantics></mml:math></inline-formula>and <inline-formula><mml:math id="mm12"><mml:semantics><mml:mrow><mml:mi mathvariant="bold-italic">β</mml:mi></mml:mrow></mml:semantics></mml:math></inline-formula>.</p>
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<p>Several shapes of the mean, variance, skewness, kurtosis, and the coefficient of variation of the LL distribution.</p>
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<p>Steps of CS-PALT under progressive Type II.</p>
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<p>Pdfs under usual and accelerated conditions.</p>
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<p>TTT plots and boxplots under usual and accelerated conditions of DATA I.</p>
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<p>TTT plots and boxplots under usual and accelerated conditions of DATA II.</p>
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26 pages, 2564 KiB  
Article
Multi-Task Forecasting of the Realized Volatilities of Agricultural Commodity Prices
by Rangan Gupta and Christian Pierdzioch
Mathematics 2024, 12(18), 2952; https://doi.org/10.3390/math12182952 - 23 Sep 2024
Viewed by 540
Abstract
Motivated by the comovement of realized volatilities (RVs) of agricultural commodity prices, we study whether multi-task forecasting algorithms improve the accuracy of out-of-sample forecasts of 15 agricultural commodities during the sample period from July 2015 to April 2023. We consider alternative multi-task stacking [...] Read more.
Motivated by the comovement of realized volatilities (RVs) of agricultural commodity prices, we study whether multi-task forecasting algorithms improve the accuracy of out-of-sample forecasts of 15 agricultural commodities during the sample period from July 2015 to April 2023. We consider alternative multi-task stacking algorithms and variants of the multivariate Lasso estimator. We find evidence of in-sample predictability but scarce evidence that multi-task forecasting improves out-of-sample forecasts relative to a classic univariate heterogeneous autoregressive (HAR)-RV model. This lack of systematic evidence of out-of-sample forecasting gains is corroborated by extensive robustness checks, including an in-depth study of the quantiles of the distributions of the RVs and subsample periods that account for increases in the total spillovers among the RVs. We also study an extended model that features the RVs of energy commodities and precious metals, but our conclusions remain unaffected. Besides offering important lessons for future research, our results are interesting for financial market participants, who rely on accurate forecasts of RVs when solving portfolio optimization and derivatives pricing problems, and policymakers, who need accurate forecasts of RVs when designing policies to mitigate the potential adverse effects of a rise in the RVs of agricultural commodity prices and the concomitant economic and political uncertainty. Full article
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<p>RVs of agricultural commodities.</p>
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<p>Full–sample correlation matrix.</p>
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<p>Full–sample estimated coefficients (baseline stacking algorithm). The forecast horizons are <math display="inline"><semantics> <mrow> <mi>h</mi> <mo>=</mo> <mn>1</mn> <mo>,</mo> <mn>5</mn> <mo>,</mo> <mn>10</mn> <mo>,</mo> <mn>20</mn> </mrow> </semantics></math> (starting in the upper-left panel).</p>
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<p>Full–sample estimated coefficients (baseline stacking algorithm). The forecast horizons are <math display="inline"><semantics> <mrow> <mi>h</mi> <mo>=</mo> <mn>1</mn> <mo>,</mo> <mn>5</mn> <mo>,</mo> <mn>10</mn> <mo>,</mo> <mn>20</mn> </mrow> </semantics></math> (starting in the upper-left panel).</p>
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<p>RMSFE ratios for the full sample (baseline stacking algorithm). RMSFE ratios for a comparison of the HAR-RV-S model (meta learner) with the HAR-RV model. An RMSFE ratio smaller than unity indicates that the meta learner produces a smaller in-sample RMSFE than the HAR-RV model. The forecast horizons are <math display="inline"><semantics> <mrow> <mi>h</mi> <mo>=</mo> <mn>1</mn> <mo>,</mo> <mn>5</mn> <mo>,</mo> <mn>10</mn> <mo>,</mo> <mn>20</mn> </mrow> </semantics></math>.</p>
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<p>RMSFE ratios for the full sample (baseline stacking algorithm). RMSFE ratios for a comparison of the HAR-RV-S model (meta learner) with the HAR-RV model. An RMSFE ratio smaller than unity indicates that the meta learner produces a smaller in-sample RMSFE than the HAR-RV model. The forecast horizons are <math display="inline"><semantics> <mrow> <mi>h</mi> <mo>=</mo> <mn>1</mn> <mo>,</mo> <mn>5</mn> <mo>,</mo> <mn>10</mn> <mo>,</mo> <mn>20</mn> </mrow> </semantics></math>.</p>
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<p>RMSFE ratios for a recursive window (baseline stacking algorithm). RMSFE ratios for a comparison of the HAR-RV-S model (meta learner) with the HAR-RV model. An RMSFE ratio smaller than unity indicates that the meta learner produces a smaller in-sample RMSFE than the HAR-RV model. The forecast horizons are <math display="inline"><semantics> <mrow> <mi>h</mi> <mo>=</mo> <mn>1</mn> <mo>,</mo> <mn>5</mn> <mo>,</mo> <mn>10</mn> <mo>,</mo> <mn>20</mn> </mrow> </semantics></math>.</p>
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<p>RMSFE ratios for a rolling window (baseline stacking algorithm). RMSFE ratios for a comparison of the HAR-RV-S model (meta learner) with the HAR-RV model. An RMSFE ratio smaller than unity indicates that the meta learner produces a smaller in-sample RMSFE than the HAR-RV model. The forecast horizons are <math display="inline"><semantics> <mrow> <mi>h</mi> <mo>=</mo> <mn>1</mn> <mo>,</mo> <mn>5</mn> <mo>,</mo> <mn>10</mn> <mo>,</mo> <mn>20</mn> </mrow> </semantics></math>.</p>
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<p>MAFE ratios for a recursive window (baseline stacking algorithm). MAFE ratios for a comparison of the HAR-RV-S model (meta learner) with the HAR-RV model. A MAFE ratio smaller than unity indicates that the meta learner produces a smaller in-sample MAFE than the HAR-RV model. The forecast horizons are <math display="inline"><semantics> <mrow> <mi>h</mi> <mo>=</mo> <mn>1</mn> <mo>,</mo> <mn>5</mn> <mo>,</mo> <mn>10</mn> <mo>,</mo> <mn>20</mn> </mrow> </semantics></math>.</p>
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<p>RMSFE ratios for a recursive window (modified stacking algorithm). RMSFE ratios for a comparison of the HAR-RV-S model (meta learner) with the HAR-RV model. An RMSFE ratio smaller than unity indicates that the meta learner produces a smaller in-sample RMSFE than the HAR-RV model. The forecast horizons are <math display="inline"><semantics> <mrow> <mi>h</mi> <mo>=</mo> <mn>1</mn> <mo>,</mo> <mn>5</mn> <mo>,</mo> <mn>10</mn> <mo>,</mo> <mn>20</mn> </mrow> </semantics></math>.</p>
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<p>RMSFE ratios for a rolling window (modified stacking algorithm). RMSFE ratios for a comparison of the HAR-RV-S model (meta learner) with the HAR-RV model. An RMSFE ratio smaller than unity indicates that the meta learner produces a smaller in-sample RMSFE than the HAR-RV model. The forecast horizons are <math display="inline"><semantics> <mrow> <mi>h</mi> <mo>=</mo> <mn>1</mn> <mo>,</mo> <mn>5</mn> <mo>,</mo> <mn>10</mn> <mo>,</mo> <mn>20</mn> </mrow> </semantics></math>.</p>
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<p>RMSFE ratios for a recursive window (multivariate shrinkage estimator). RMSFE ratios for a comparison of the HAR-RV-S model (meta learner) with the HAR-RV model. An RMSFE ratio smaller than unity indicates that the meta learner produces a smaller in-sample RMSFE than the HAR-RV model. The forecast horizons are <math display="inline"><semantics> <mrow> <mi>h</mi> <mo>=</mo> <mn>1</mn> <mo>,</mo> <mn>5</mn> <mo>,</mo> <mn>10</mn> <mo>,</mo> <mn>20</mn> </mrow> </semantics></math>.</p>
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<p>RMSFE ratios for a rolling window (multivariate shrinkage estimator). RMSFE ratios for a comparison of the HAR-RV-S model (meta learner) with the HAR-RV model. An RMSFE ratio smaller than unity indicates that the meta learner produces a smaller in-sample RMSFE than the HAR-RV model. The forecast horizons are <math display="inline"><semantics> <mrow> <mi>h</mi> <mo>=</mo> <mn>1</mn> <mo>,</mo> <mn>5</mn> <mo>,</mo> <mn>10</mn> <mo>,</mo> <mn>20</mn> </mrow> </semantics></math>.</p>
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<p>Quantile-based RMSFE ratios for a recursive window (baseline stacking algorithm). RMSFE ratios for different quantiles of the realizations of RV. RMSFE ratios for a comparison of the HAR-RV-S model (meta learner) with the HAR-RV model. An RMSFE ratio smaller than unity indicates that the meta learner produces a smaller in-sample RMSFE than the HAR-RV model. The forecast horizons are <math display="inline"><semantics> <mrow> <mi>h</mi> <mo>=</mo> <mn>1</mn> <mo>,</mo> <mn>5</mn> <mo>,</mo> <mn>10</mn> <mo>,</mo> <mn>20</mn> </mrow> </semantics></math>.</p>
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<p>Quantile-based RMSFE ratios for a rolling window (baseline stacking algorithm). RMSFE ratios for different quantiles of the realizations of RV. RMSFE ratios for a comparison of the HAR-RV-S model (meta learner) with the HAR-RV model. An RMSFE ratio smaller than unity indicates that the meta learner produces a smaller in-sample RMSFE than the HAR-RV model. The forecast horizons are <math display="inline"><semantics> <mrow> <mi>h</mi> <mo>=</mo> <mn>1</mn> <mo>,</mo> <mn>5</mn> <mo>,</mo> <mn>10</mn> <mo>,</mo> <mn>20</mn> </mrow> </semantics></math>.</p>
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<p>Rolling-window estimates of a spillover index. The total dynamic spillover index is derived from a VAR(5) model estimated using a rolling estimation window with a length of 1000 observations and a 10-step-ahead generalized forecast error variance decomposition.</p>
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<p>Subsample analysis for a recursive window (modified stacking algorithm). The panels on the left-hand side summarize the results for the first subsample. The panels on the right-hand side summarize the results for the first subsample. The first subsample comprises the first 450 out-of-sample forecasts. The second subsample is obtained upon deleting the first 450 out-of-sample forecasts. RMSFE ratios for a comparison of the HAR-RV-S model (meta learner) with the HAR-RV model. An RMSFE ratio smaller than unity indicates that the meta learner produces a smaller in-sample RMSFE than the HAR-RV model. The forecast horizons are <math display="inline"><semantics> <mrow> <mi>h</mi> <mo>=</mo> <mn>1</mn> <mo>,</mo> <mn>5</mn> <mo>,</mo> <mn>10</mn> <mo>,</mo> <mn>20</mn> </mrow> </semantics></math>.</p>
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<p>Subsample analysis for a rolling window (modified stacking algorithm). The panels on the left-hand side summarize the results for the first subsample. The panels on the right-hand side summarize the results for the first subsample. The first subsample comprises the first 450 out-of-sample forecasts. The second subsample is obtained upon deleting the first 450 out-of-sample forecasts. RMSFE ratios for a comparison of the HAR-RV-S model (meta learner) with the HAR-RV model. An RMSFE ratio smaller than unity indicates that the meta learner produces a smaller in-sample RMSFE than the HAR-RV model. The forecast horizons are <math display="inline"><semantics> <mrow> <mi>h</mi> <mo>=</mo> <mn>1</mn> <mo>,</mo> <mn>5</mn> <mo>,</mo> <mn>10</mn> <mo>,</mo> <mn>20</mn> </mrow> </semantics></math>.</p>
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<p>Subsample analysis for a rolling window (modified stacking algorithm). The panels on the left-hand side summarize the results for the first subsample. The panels on the right-hand side summarize the results for the first subsample. The first subsample comprises the first 450 out-of-sample forecasts. The second subsample is obtained upon deleting the first 450 out-of-sample forecasts. RMSFE ratios for a comparison of the HAR-RV-S model (meta learner) with the HAR-RV model. An RMSFE ratio smaller than unity indicates that the meta learner produces a smaller in-sample RMSFE than the HAR-RV model. The forecast horizons are <math display="inline"><semantics> <mrow> <mi>h</mi> <mo>=</mo> <mn>1</mn> <mo>,</mo> <mn>5</mn> <mo>,</mo> <mn>10</mn> <mo>,</mo> <mn>20</mn> </mrow> </semantics></math>.</p>
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<p>RVs of energy commodities.</p>
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<p>RVs of precious metals.</p>
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<p>Full–sample correlation matrix (extended sample of commodities).</p>
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<p>Rolling-window estimates of a spillover index (extended sample of commodities). The total dynamic spillover index is derived from a VAR(5) model estimated using a rolling estimation window with a length of 1000 observations and a 10-step-ahead generalized forecast error variance decomposition.</p>
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<p>Full-sample RMSFE ratios (modified stacking estimator). RMSFE ratios for a comparison of the HAR-RV-S model (meta learner) with the HAR-RV model. An RMSFE ratio smaller than unity indicates that the meta learner produces a smaller in-sample RMSFE than the HAR-RV model. The forecast horizons are <math display="inline"><semantics> <mrow> <mi>h</mi> <mo>=</mo> <mn>1</mn> <mo>,</mo> <mn>5</mn> <mo>,</mo> <mn>10</mn> <mo>,</mo> <mn>20</mn> </mrow> </semantics></math>.</p>
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<p>RMSFE ratios for a recursive window (modified stacking estimator). RMSFE ratios for a comparison of the HAR-RV-S model (meta learner) with the HAR-RV model. An RMSFE ratio smaller than unity indicates that the meta learner produces a smaller in-sample RMSFE than the HAR-RV model. The forecast horizons are <math display="inline"><semantics> <mrow> <mi>h</mi> <mo>=</mo> <mn>1</mn> <mo>,</mo> <mn>5</mn> <mo>,</mo> <mn>10</mn> <mo>,</mo> <mn>20</mn> </mrow> </semantics></math>.</p>
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<p>RMSFE ratios for a rolling window (modified stacking estimator). RMSFE ratios for a comparison of the HAR-RV-S model (meta learner) with the HAR-RV model. An RMSFE ratio smaller than unity indicates that the meta learner produces a smaller in-sample RMSFE than the HAR-RV model. The forecast horizons are <math display="inline"><semantics> <mrow> <mi>h</mi> <mo>=</mo> <mn>1</mn> <mo>,</mo> <mn>5</mn> <mo>,</mo> <mn>10</mn> <mo>,</mo> <mn>20</mn> </mrow> </semantics></math>.</p>
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16 pages, 623 KiB  
Article
Unveiling the Age Factor: The Influence of Cabinet Members’ Age on Waste Electrical and Electronic Equipment Recycling Rates in European Nations
by Erdal Arslan, Musa Şanal, Cuneyt Koyuncu and Rasim Yilmaz
Sustainability 2024, 16(18), 8202; https://doi.org/10.3390/su16188202 - 20 Sep 2024
Viewed by 595
Abstract
Utilizing panel quantile regression on an unbalanced dataset for 30 European countries from 2008 to 2018, this article seeks to investigate how the age of cabinet members influences e-waste recycling rates in European countries, alongside other relevant factors. Prior research has overlooked the [...] Read more.
Utilizing panel quantile regression on an unbalanced dataset for 30 European countries from 2008 to 2018, this article seeks to investigate how the age of cabinet members influences e-waste recycling rates in European countries, alongside other relevant factors. Prior research has overlooked the age of cabinet members as a determinant of e-waste recycling. By addressing this gap, this study introduces a novel factor that could impact e-waste recycling rates. Thus, this study provides insights into how the demographic characteristics of parliament members, particularly the age of cabinet members, impact environmental improvement, as indicated by e-waste recycling rates. Estimation results indicate the existence of a nonlinear relationship (i.e., an inverted U-shaped environmental Kuznets curve) between the age of cabinet members and the e-waste recycling rate, rather than a linear relationship. The calculated average turning point age is 49.087, indicating that the e-waste recycling rate increases as the age of cabinet members rises until reaching 49.087, after which the e-waste recycling rate declines. Overall, this study underscores the importance of the demographic characteristics of parliament members, particularly the age of cabinet members, in shaping e-waste recycling policies and environmental sustainability efforts. It emphasizes that the age of cabinet members and generational perspectives can influence their awareness, understanding, and commitment to addressing contemporary challenges such as e-waste. Full article
(This article belongs to the Section Waste and Recycling)
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<p>The rate of WEEE recycling in EU countries (2018).</p>
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<p>Inverted U-shaped relationship between the age of cabinet members and the rate of WEEE recycling.</p>
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43 pages, 2810 KiB  
Article
Corporate Financial Performance vs. Corporate Sustainability Performance, between Earnings Management and Process Improvement
by Valentin Burcă, Oana Bogdan, Ovidiu-Constantin Bunget and Alin-Constantin Dumitrescu
Sustainability 2024, 16(17), 7744; https://doi.org/10.3390/su16177744 - 5 Sep 2024
Viewed by 856
Abstract
The main objective of the paper is to assess the relationship between firms’ financial resilience and firms’ strategic sustainable development vulnerabilities, in the context of implications of the COVID-19 pandemic on firms’ business environment. Background: The last decade has emphasized an increase in [...] Read more.
The main objective of the paper is to assess the relationship between firms’ financial resilience and firms’ strategic sustainable development vulnerabilities, in the context of implications of the COVID-19 pandemic on firms’ business environment. Background: The last decade has emphasized an increase in business models’ uncertainty and risk exposure. The COVID-19 pandemic has highlighted the awareness in this direction, especially in a changing context, that looks more and more for corporate sector operations’ orientation towards sustainable development. The question we would address in this paper is how the nexus between corporate sustainability performance and corporate financial resilience is affected by management decision through process improvements, product quality assurance, or managers’ preference to improve corporate financials by earnings management practice instead, especially in the context of specific corporate financial risk management. Methods: The data are extracted from the Refinitiv database. The sample is limited to 275 European Union listed firms, selected based on data availability. The empirical analysis consists of an OLS multiple regression. For robustness purposes, a quantile regression model is estimated as well. Results: The approach considers implications of the pandemic on firms’ business environment and earnings management accounting based policies and strategies as well. The result suggests that alignment to sustainability frameworks lead to the deterioration of firms’ financial resilience. Similar results show the negative impact of firms’ financial vulnerability (credit default risk) on firms’ financial resilience. Instead, the risk of bankruptcy, firms’ liquidity, or high product quality and business process improvement determine the positive impact on firms’ financial resilience. Conclusions: The study highlights several insights both for management and policy makers. First, the results underline the relevance of management’s choice for earnings management on ensuring firms’ financial resilience, which ask for better corporate governance and high-quality and effective institutional regulatory and enforcement mechanisms. Second, the paper brings evidence on the impact of the COVID-19 pandemic on firms’ financial sustainable development. Third, the study emphasizes the importance of the efforts of corporate process improvements and high-quality products on generating value-add, by looking on the relevance of those drivers on the level of corporate economic value-add, a measure that limits the impact of discretionary management accrual-based accounting choices on our discussion. Full article
(This article belongs to the Special Issue Management Control Systems to Sustainability)
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<p>Theoretical research framework. Source: authors’ projection.</p>
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<p>Empirical analysis methodological steps. Source: authors’ projection.</p>
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<p>Sample composition. Source: authors’ projection.</p>
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<p>Time series on the evolution of EVA on country basis. Source: authors’ projection.</p>
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<p>Time series on the evolution of EVA on industry basis. Source: authors’ projection.</p>
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<p>Industry effects on variation of economic value added in pandemic period. Source: authors’ projection.</p>
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23 pages, 1980 KiB  
Article
Unit-Power Half-Normal Distribution Including Quantile Regression with Applications to Medical Data
by Karol I. Santoro, Yolanda M. Gómez, Darlin Soto and Inmaculada Barranco-Chamorro
Axioms 2024, 13(9), 599; https://doi.org/10.3390/axioms13090599 - 2 Sep 2024
Viewed by 539
Abstract
In this paper, we present the unit-power half-normal distribution, derived from the power half-normal distribution, for data analysis in the open unit interval. The statistical properties of the unit-power half-normal model are described in detail. Simulation studies are carried out to evaluate the [...] Read more.
In this paper, we present the unit-power half-normal distribution, derived from the power half-normal distribution, for data analysis in the open unit interval. The statistical properties of the unit-power half-normal model are described in detail. Simulation studies are carried out to evaluate the performance of the parameter estimators. Additionally, we implement the quantile regression for this model, which is applied to two real healthcare data sets. Our findings suggest that the unit power half-normal distribution provides a robust and flexible alternative for existing models for proportion data. Full article
(This article belongs to the Special Issue Probability, Statistics and Estimations, 2nd Edition)
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<p>Pdf and cdf for UPHN<math display="inline"><semantics> <mrow> <mo>(</mo> <mi>σ</mi> <mo>=</mo> <mn>1</mn> <mo>,</mo> <mi>α</mi> <mo>)</mo> </mrow> </semantics></math> model with different values of <math display="inline"><semantics> <mi>α</mi> </semantics></math>.</p>
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<p>Pdf and cdf for UPHN<math display="inline"><semantics> <mrow> <mo>(</mo> <mi>σ</mi> <mo>,</mo> <mi>α</mi> <mo>)</mo> </mrow> </semantics></math> model for some values of parameters <math display="inline"><semantics> <mi>σ</mi> </semantics></math> and <math display="inline"><semantics> <mi>α</mi> </semantics></math>.</p>
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<p>Survival and hazard functions for <math display="inline"><semantics> <mrow> <mrow> <mi mathvariant="normal">U</mi> <mi mathvariant="normal">P</mi> <mi mathvariant="normal">H</mi> <mi mathvariant="normal">N</mi> </mrow> <mo>(</mo> <mi>σ</mi> <mo>,</mo> <mi>α</mi> <mo>)</mo> </mrow> </semantics></math> model for some values of parameters <math display="inline"><semantics> <mi>σ</mi> </semantics></math> and <math display="inline"><semantics> <mi>α</mi> </semantics></math>.</p>
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<p>Plots of the MacGillivray skewness coefficient in UPHN model.</p>
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<p>Plots of the Moors kurtosis coefficient for the <math display="inline"><semantics> <mrow> <mi mathvariant="normal">U</mi> <mi mathvariant="normal">P</mi> <mi mathvariant="normal">H</mi> <mi mathvariant="normal">N</mi> </mrow> </semantics></math> model.</p>
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<p>QQ plots with envelopes of Cox–Snell residuals for the indicated 100 <span class="html-italic">p</span>-th quantile level and Cramér-von Mises test <span class="html-italic">p</span>-value for residuals obtained from different distributions (uphn, kum, ughnx, ugompertz, and uweibull) with body fat data.</p>
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<p>QQ plots with envelopes of Cox–Snell residuals for the proposed 100 p-th quantile level and Cramér–von Mises test <span class="html-italic">p</span>-value for residuals obtained from different distributions (uphn, kum, ughnx, ugompertz, and uweibull) with PBSC data.</p>
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15 pages, 23629 KiB  
Article
Machine Learning Methods for Evaluation of Technical Factors of Spraying in Permanent Plantations
by Vjekoslav Tadić, Dorijan Radočaj and Mladen Jurišić
Agronomy 2024, 14(9), 1977; https://doi.org/10.3390/agronomy14091977 - 1 Sep 2024
Viewed by 570
Abstract
Considering the demand for the optimization of the technical factors of spraying for a greater area coverage and minimal drift, field tests were carried out to determine the interaction between the area coverage, number of droplets per cm2, droplet diameter, and [...] Read more.
Considering the demand for the optimization of the technical factors of spraying for a greater area coverage and minimal drift, field tests were carried out to determine the interaction between the area coverage, number of droplets per cm2, droplet diameter, and drift. The studies were conducted with two different types of sprayers (axial and radial fan) in an apple orchard and a vineyard. The technical factors of the spraying interactions were nozzle type (ISO code 015, code 02, and code 03), working speed (6 and 8 km h−1), and spraying norm (250–400 L h−1). The airflow of both sprayers was adjusted to the plantation leaf mass and the working pressure was set for each repetition separately. A method using water-sensitive paper and a digital image analysis was used to collect data on coverage factors. The data from the field research were processed using four machine learning models: quantile random forest (QRF), support vector regression with radial basis function kernel (SVR), Bayesian Regularization for Feed-Forward Neural Networks (BRNN), and Ensemble Machine Learning (ENS). Nozzle type had the highest predictive value for the properties of number of droplets per cm2 (axial = 69.1%; radial = 66.0%), droplet diameter (axial = 30.6%; radial = 38.2%), and area coverage (axial = 24.6%; radial = 34.8%). Spraying norm had the greatest predictive value for area coverage (axial = 43.3%; radial = 26.9%) and drift (axial = 72.4%; radial = 62.3%). Greater coverage of the treated area and a greater number of droplets were achieved with the radial sprayer, as well as less drift. The accuracy of the machine learning model for the prediction of the treated surface showed a satisfactory accuracy for most properties (R2 = 0.694–0.984), except for the estimation of the droplet diameter for an axial sprayer (R2 = 0.437–0.503). Full article
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<p>The workflow of the proposed leaf spraying coverage prediction based on an ensemble machine learning approach.</p>
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<p>Apple orchard (<b>a</b>) and vineyard (<b>b</b>) in field research.</p>
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<p>Axial (<b>a</b>) and radial (<b>b</b>) sprayer.</p>
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<p>Water-sensitive papers (WSPs).</p>
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<p>Boxplots for distribution of technical factors of spraying according to coverage factors.</p>
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<p>The relative variable importance of four independent technical factors of spraying used for the prediction of spraying coverage factors.</p>
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21 pages, 7364 KiB  
Article
Deriving Tropical Cyclone-Associated Flood Hazard Information Using Clustered GPM-IMERG Rainfall Signatures: Case Study in Dominica
by Catherine Nabukulu, Victor G. Jetten, Janneke Ettema, Bastian van den Bout and Reindert J. Haarsma
Atmosphere 2024, 15(9), 1042; https://doi.org/10.3390/atmos15091042 - 29 Aug 2024
Viewed by 864
Abstract
Various stakeholders seek effective methods to communicate the potential impacts of tropical cyclone (TC) rainfall and subsequent flood hazards. While current methods, such as Intensity–Duration–Frequency curves, offer insights, they do not fully capture TC rainfall complexity and variability. This research introduces an innovative [...] Read more.
Various stakeholders seek effective methods to communicate the potential impacts of tropical cyclone (TC) rainfall and subsequent flood hazards. While current methods, such as Intensity–Duration–Frequency curves, offer insights, they do not fully capture TC rainfall complexity and variability. This research introduces an innovative workflow utilizing GPM-IMERG satellite precipitation estimates to cluster TC rainfall spatial–temporal patterns, thereby illustrating their potential for flood hazard assessment by simulating associated flood responses. The methodology is tested using rainfall time series from a single TC as it traversed a 500 km diameter buffer zone around Dominica. Spatial partitional clustering with K-means identified the spatial clusters of rainfall time series with similar temporal patterns. The optimal value of K = 4 was most suitable for grouping the rainfall time series of the tested TC. Representative precipitation signals (RPSs) from the quantile analysis generalized the cluster temporal patterns. RPSs served as the rainfall input for the openLISEM, an event-based hydrological model simulating related flood characteristics. The tested TC exhibited three spatially distinct levels of rainfall magnitude, i.e., extreme, intermediate, and least intense, each resulting in different flood responses. Therefore, TC rainfall varies in space and time, affecting local flood hazards; flood assessments should incorporate variability to improve response and recovery. Full article
(This article belongs to the Special Issue Advances in Rainfall-Induced Hazard Research)
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<p>Flow chart for the proof of concept showing the sequence of analyses that form the developed workflow.</p>
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<p>Illustration of the procedure for selecting cluster representative precipitation signals. (<b>a</b>) Visualization of a selection of pixel rainfall time series of a given cluster. (<b>b</b>) Rainfall series after applying a starting threshold. (<b>c</b>) Example for timestep quantile series for probabilities 0.5, 0.75, and 0.9 calculated after applying the starting threshold.</p>
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<p>Map of the region of interest defined by the buffer boundary. The cumulative total rainfall for any given pixel in the study area over the selected time window is represented with a green-red colour ramp. The clusters labelled T1, T2, T3, T4, and T5 resulted from using <span class="html-italic">K</span> = 5 when conducting the spatial clustering analysis of the pixel rainfall time series. The bottom inset is the location of the Grand Bay catchment for which the flood modelling was performed.</p>
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<p>Elbow graph of the optimal <span class="html-italic">K</span> values used to experiment with the developed workflow. The total within-cluster sum of squares (TWSS) is the total sum of the squared distances between the data points and the centroid of their assigned clusters.</p>
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<p>The outcome of the time alignment and quantile analysis when applying <span class="html-italic">K</span> = 5. Only Q<sub>0.5</sub> and Q<sub>0.75</sub> were selected for each cluster as the representative precipitation signals (RPSs). Clusters T1, T3, T4, and T5 are in graphs (<b>a</b>), (<b>b</b>), (<b>c</b>), and (<b>d</b>), respectively.</p>
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<p>Flood depth maps for Grand Bay catchment on Dominica as simulated using the Q<sub>0.75</sub> RPSs for clusters T1, T3, and T4 resulting from applying <span class="html-italic">K</span> = 4.</p>
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<p>Precipitation time series (intensity/duration) and cumulative plots of the TC-associated rainfall scenarios for TS Erika resulting from <span class="html-italic">K</span> = 4. The blue bar graphs represent the half-hourly rainfall intensities, and the black line is for the cumulative precipitation. (<b>a</b>) Extreme, (<b>b</b>) intermediate, and (<b>c</b>) least intense.</p>
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<p>Plots of (<b>a</b>) the average hourly rainfall on Dominica due to TS Erika and the line plot of the cumulative rain from <a href="#atmosphere-15-01042-t001" class="html-table">Table 1</a> of the report by [<a href="#B28-atmosphere-15-01042" class="html-bibr">28</a>]. Plots (<b>b</b>,<b>c</b>) compare the output cluster-based design events with the design storms derived from IDF curves available for the region in <a href="#atmosphere-15-01042-f003" class="html-fig">Figure 3</a> from [<a href="#B20-atmosphere-15-01042" class="html-bibr">20</a>] by applying the ABM. The line plots (<b>b</b>,<b>c</b>) are the corresponding cumulative rainfall, black for the output cluster-based design events and orange for the design storms.</p>
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<p>The maps below represent the cluster boundaries resulting from applying <span class="html-italic">K</span> = 4 (<b>left</b>) and <span class="html-italic">K</span> = 3 (<b>right</b>) when conducting the spatial partitional clustering.</p>
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34 pages, 2103 KiB  
Article
Green Innovation at the Crossroads of Financial Development, Resource Depletion, and Urbanization: Paving the Way to a Sustainable Future from the Perspective of an MM-QR Approach
by Wen Liu and Muhammad Waqas
Sustainability 2024, 16(16), 7127; https://doi.org/10.3390/su16167127 - 20 Aug 2024
Viewed by 907
Abstract
Global warming has become a big problem around the world, and it is because of what people do. As a possible answer, countries are looking for ways to keep their economies growing and invest in technologies that use clean energy. Therefore, the notion [...] Read more.
Global warming has become a big problem around the world, and it is because of what people do. As a possible answer, countries are looking for ways to keep their economies growing and invest in technologies that use clean energy. Therefore, the notion of carbon neutrality has emerged as a crucial policy strategy for nations to attain sustainable development. This study expands the existing discussions on carbon neutrality by investigating the influence of key factors, including green innovation, financial development, natural resources depletion, trade openness, institutional quality, growth, and urbanization on the progress made towards attaining a carbon neutral state in the BRICS nations. This study considers the Method of Moment Quantile-Regression (MM-QR) and Prais–Winsten correlated panel corrected standard errors (PCSEs) estimators to investigate the study objectives over the period of 1990–2021. Under the investigated outcomes, this study validated the significant role of urbanization and growth in carbon neutrality. On the other hand, this study finds the positive role of openness, green innovation, resource depletion, institutional quality, and financial development on environmental deterioration. However, under a systematic analysis, this study utilizes different proxies of the financial sector, for instance, financial complexity, financial efficiency, financial stability, and domestic credit by financial sector, and provides interesting outcomes. Based on these outcomes, this study also provides suggestions to attain desired levels of sustainability. Full article
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<p>Carbon emissions in BRICS economies (World Bank Open Data).</p>
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<p>Historical trend of financial development (World Bank Open Data).</p>
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<p>Cross-sectional independence.</p>
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<p>Distribution of factors in quantiles.</p>
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27 pages, 350 KiB  
Article
The Impact of Land Transfer on Sustainable Agricultural Development from the Perspective of Green Total Factor Productivity
by Yangchenhao Wu and Wang Zhang
Sustainability 2024, 16(16), 7076; https://doi.org/10.3390/su16167076 - 18 Aug 2024
Viewed by 829
Abstract
China’s agricultural sector is transitioning from extensive management to intensive management, and land transfer brings about changes in land use and management methods, which may encourage the agricultural sector to enter a sustainable development track, but this mechanism has not been effectively proven. [...] Read more.
China’s agricultural sector is transitioning from extensive management to intensive management, and land transfer brings about changes in land use and management methods, which may encourage the agricultural sector to enter a sustainable development track, but this mechanism has not been effectively proven. Using the SBM-GML index to construct a green total factor productivity index to measure the level of sustainable agricultural development in each province (or autonomous region or municipality directly under the central government) and provincial panel data from 2010 to 2022, we applied a panel interactive fixed-effects model to empirically test the impact of land transfer on sustainable agricultural development, with a focus on analyzing the heterogeneity and related mechanisms of this impact. The results indicate that (1) land transfer significantly promotes sustainable agricultural development, and this conclusion still held true after robustness tests such as controlling for regional omitted variables, replacing dependent variables, changing the sample size, IV estimation, and GMM estimation. (2) The mechanism testing found that land transfer mainly promotes sustainable agricultural development by increasing the desirable output, and has no significant effect on reducing non-point source pollution. At the same time, land transfer mainly improves the desirable output through factor allocation effects rather than scale operation effects, thereby promoting sustainable agricultural development. (3) The heterogeneity analysis found that the higher the quantile of agricultural development level is, the weaker the role of land transfer in promoting sustainable agricultural development, indicating that land transfer has a greater impact on areas with poor agricultural development foundations, and areas with poor agricultural development foundations are more likely to obtain sustainable development space through land transfer. The impact of different land transfer methods and land transfer objects on sustainable agricultural development was heterogeneous. Compared with non-market transfer methods such as exchange and transfer, market-oriented transfer methods such as leasing and equity had a more significant impact on sustainable agricultural development. Compared to transferring land to ordinary farmers, transferring land to new business entities such as family farms, professional cooperatives, and enterprises can significantly promote sustainable agricultural development. Full article
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