Critérios de seleção para incremento de uniformidade de produção em bovinos de corte

Coordenação de Aperfeiçoamento de Pessoal de Nível Superior (CAPES)

Interação genótipo-ambiente para a produção de leite em bubalinos no Brasil e na Colômbia

Fundação de Amparo à Pesquisa do Estado de São Paulo (FAPESP)

Comparação entre os estimadores de mínimos quadrados ordinários e mínimos desvios absolutos em modelos de regressão linear simples -: uma aplicação na energia na agricultura

Pós-graduação em Agronomia (Energia na Agricultura) - FCA

Efeito da interação genótipo ambiente, sob a forma de heterogeneidade de variâncias entre rebanhos

Foram simuladas estruturas de dados em modelos mistos representando o teste de 100 reprodutores, sendo cada reprodutor acasalado com 10 matrizes (total de 1000 matrizes), originando em cada acasalamento 2 proles, totalizando 2000 proles (vinte proles por reprodutor). De cada combinação reprodutor e matriz, dez proles tiveram seu fenótipo expresso no ambiente de baixa produção (Estrato 1) e, a outra metade, no ambiente de alta produção (Estrato 2). A simulação foi realizada de forma a representar diferentes situações de presença de heterogeneidade de variâncias, combinando-se as origens da heterogeneidade, de natureza genética e ambiental. Na presença de heterogeneidade residual, o valor estimado para o componente de variância residual, considerando homogeneidade de variâncias se aproximou do valor médio das variâncias entre os estratos. Houve superestimação, também, do componente de variância genético aditivo. Ao simular heterogeneidade de variância de origem genética, observou-se que a estimação desse componente situou-se em valor intermediário aos simulados. Nessa situação, o componente de variância residual estimado foi próximo do valor simulado, indicando que a heterogeneidade de variâncias quando proveniente de fatores genéticos, não interfere, substancialmente, sobre e estimação do componente de variância residual. Na simulação de dados com presença de heterogeneidade tanto de origem genética quanto ambiental (estrutura de dados 4), conduziu a estimação de componentes de variâncias intermediários aos valores simulados em cada estrato. Assim, observa-se que, mesmo quando os reprodutores apresentam proles bem distribuídas em ambos os estratos, a heterogeneidade de variância proveniente de fatores não genético provoca distorções sobre a estimação da variância genética aditiva. Mas por outro lado, quando a heterogeneidade de variância é decorrente de fatores genéticos, não há grande interferência sobre a estimativa da variância residual, tal comportamento pode ser explicado pela incorporação da matriz de parentesco na estimação do componente de variância genético aditivo, possibilitando discriminar melhor a origem da diferenças entre variâncias. Na estrutura onde a variância residual foi heterogênea a estimativa de herdabilidade foi menor em relação à estrutura de homogeneidade de variâncias. Por outro lado, quando somente a variância genética aditiva foi heterogênea, a estimativa de herdabilidade, considerando-se apenas o estrato de alta variabilidade genética, foi inflacionada pela superestimação da variância genética aditiva. No entanto, a estimativa de herdabilidade obtida, desconsiderando essa fonte de heterogeneidade de variância, foi próxima à situação de homogeneidade de variância, indicando que, quando os reprodutores possuem boa distribuição de proles em diferentes ambientes, as estimativas relacionadas ao efeito genético são ponderadas pelo desempenho dos animais em cada ambiente. As correlações de Spearman e de Pearson entre os valores genéticos preditos dos reprodutores, para todas as situações, foram maiores que 0,90. O resultado indica que, mesmo havendo presença de heterogeneidade de variância genética e/ou ambiental, se os reprodutores possuem proles bem distribuídas entre os ambientes (estratos heterogêneos) a classificação do mérito genético não se altera, o que era esperado, pois em análises unicarácter, quando ocorre uma fonte de viés na avaliação genética, ela é comum a todos os indivíduos. Na situação em que foi imposta a estrutura de dados à presença de heterogeneidade de variância residual com número de número desigual de proles por reprodutor nos estratos, provocou superestimação dos componentes de variância. Porém mesmo havendo alteração na magnitude dos valores genéticos preditos para os reprodutores, a heterogeneidade de variância não alterou a classificação entre os reprodutores todas as correlações de ordem foram próximas à unidade. O efeito da heterogeneidade de variância, oriunda de fatores ambientais, ocasiona em maiores distorções sobre a avaliação genética animal, em relação, quando a mesma é proveniente de causas genéticas. A conexidade genética entre diferentes ambientes, dilui o efeito da heterogeneidade de variância, tanto de origem genética, quanto ambiental, na predição de valores genéticos dos reprodutores.

Persistência da lactação e Influência da estrutura de dados sobre a estimação de parâmetros genéticos para a produção de leite de bovinos da raça Holandesa

Conselho Nacional de Desenvolvimento Científico e Tecnológico (CNPq)

Bayesian analysis of random regression models using B-splines to model test-day milk yield of Holstein cattle in Brazil

The objective of this paper is to model variations in test-day milk yields of first lactations of Holstein cows by RR using B-spline functions and Bayesian inference in order to fit adequate and parsimonious models for the estimation of genetic parameters. They used 152,145 test day milk yield records from 7317 first lactations of Holstein cows. The model established in this study was additive, permanent environmental and residual random effects. In addition, contemporary group and linear and quadratic effects of the age of cow at calving were included as fixed effects. Authors modeled the average lactation curve of the population with a fourth-order orthogonal Legendre polynomial. They concluded that a cubic B-spline with seven random regression coefficients for both the additive genetic and permanent environment effects was to be the best according to residual mean square and residual variance estimates. Moreover they urged a lower order model (quadratic B-spline with seven random regression coefficients for both random effects) could be adopted because it yielded practically the same genetic parameter estimates with parsimony. (C) 2012 Elsevier B.V. All rights reserved.

The Importance of Scale for Spatial-confounding Bias and Precision of Spatial Regression Estimators

Increasingly, regression models are used when residuals are spatially correlated. Prominent examples include studies in environmental epidemiology to understand the chronic health effects of pollutants. I consider the effects of residual spatial structure on the bias and precision of regression coefficients, developing a simple framework in which to understand the key issues and derive informative analytic results. When the spatial residual is induced by an unmeasured confounder, regression models with spatial random effects and closely-related models such as kriging and penalized splines are biased, even when the residual variance components are known. Analytic and simulation results show how the bias depends on the spatial scales of the covariate and the residual; bias is reduced only when there is variation in the covariate at a scale smaller than the scale of the unmeasured confounding. I also discuss how the scales of the residual and the covariate affect efficiency and uncertainty estimation when the residuals can be considered independent of the covariate. In an application on the association between black carbon particulate matter air pollution and birth weight, controlling for large-scale spatial variation appears to reduce bias from unmeasured confounders, while increasing uncertainty in the estimated pollution effect.

Spatial distribution of the soil carbon pool in a Holm oak dehesa in Spain

Aims Dehesas are agroforestry systems characterized by scattered trees among pastures, crops and/or fallows. A study at a Spanish dehesa has been carried out to estimate the spatial distribution of the soil organic carbon stock and to assess the influence of the tree cover. Methods The soil organic carbon stock was estimated from the five uppermost cm of themineral soil with high spatial resolution at two plots with different grazing intensities. The Universal Kriging technique was used to assess the spatial distribution of the soil organic carbon stocks, using tree coverage within a buffering area as an auxiliary variable. Results A significant positive correlation between tree presence and soil organic carbon stocks up to distances of around 8 m from the trees was found. The tree crown cover within a buffer up to a distance similar to the crown radius around the point absorbed 30 % of the variance in the model for both grazing intensities, but residual variance showed stronger spatial autocorrelation under regular grazing conditions. Conclusions Tree cover increases soil organic carbon stocks, and can be satisfactorily estimated by means of crown parameters. However, other factors are involved in the spatial pattern of the soil organic carbon distribution. Livestock plays an interactive role together with tree presence in soil organic carbon distribution.

Comparison of Airborne Laser Scanning Methods for Estimating Forest Structure Indicators Based on Lorenz Curves

The purpose of this study was to compare a number of state-of-the-art methods in airborne laser scan- ning (ALS) remote sensing with regards to their capacity to describe tree size inequality and other indi- cators related to forest structure. The indicators chosen were based on the analysis of the Lorenz curve: Gini coefficient ( GC ), Lorenz asymmetry ( LA ), the proportions of basal area ( BALM ) and stem density ( NSLM ) stocked above the mean quadratic diameter. Each method belonged to one of these estimation strategies: (A) estimating indicators directly; (B) estimating the whole Lorenz curve; or (C) estimating a complete tree list. Across these strategies, the most popular statistical methods for area-based approach (ABA) were used: regression, random forest (RF), and nearest neighbour imputation. The latter included distance metrics based on either RF (NN–RF) or most similar neighbour (MSN). In the case of tree list esti- mation, methods based on individual tree detection (ITD) and semi-ITD, both combined with MSN impu- tation, were also studied. The most accurate method was direct estimation by best subset regression, which obtained the lowest cross-validated coefficients of variation of their root mean squared error CV(RMSE) for most indicators: GC (16.80%), LA (8.76%), BALM (8.80%) and NSLM (14.60%). Similar figures [CV(RMSE) 16.09%, 10.49%, 10.93% and 14.07%, respectively] were obtained by MSN imputation of tree lists by ABA, a method that also showed a number of additional advantages, such as better distributing the residual variance along the predictive range. In light of our results, ITD approaches may be clearly inferior to ABA with regards to describing the structural properties related to tree size inequality in for- ested areas.

The optimal measure of allelic association

Allelic association between pairs of loci is derived in terms of the association probability ρ as a function of recombination θ, effective population size N, linear systematic pressure v, and time t, predicting both ρrt, the decrease of association from founders and ρct, the increase by genetic drift, with ρt = ρrt + ρct. These results conform to the Malecot equation, with time replaced by distance on the genetic map, or on the physical map if recombination in the region is uniform. Earlier evidence suggested that ρ is less sensitive to variations in marker allele frequencies than alternative metrics for which there is no probability theory. This robustness is confirmed for six alternatives in eight samples. In none of these 48 tests was the residual variance as small as for ρ. Overall, efficiency was less than 80% for all alternatives, and less than 30% for two of them. Efficiency of alternatives did not increase when information was estimated simultaneously. The swept radius within which substantial values of ρ are conserved lies between 385 and 893 kb, but deviation of parameters between measures is enormously significant. The large effort now being devoted to allelic association has little value unless the ρ metric with the strongest theoretical basis and least sensitivity to marker allele frequencies is used for mapping of marker association and localization of disease loci.

Genetic effects on alcohol dependence risk: re-evaluating the importance of psychiatric and other heritable risk factors

Background. Genetic influences have been shown to play a major role in determining the risk of alcohol dependence (AD) in both women and men; however, little attention has been directed to identifying the major sources of genetic variation in AD risk. Method. Diagnostic telephone interview data from young adult Australian twin pairs born between 1964 and 1971 were analyzed. Cox regression models were fitted to interview data from a total of 2708 complete twin pairs (690 MZ female, 485 MZ male, 500 DZ female, 384 DZ male, and 649 DZ female/male pairs). Structural equation models were fitted to determine the extent of residual genetic and environmental influences on AD risk while controlling for effects of sociodemographic and psychiatric predictors on risk. Results. Risk of AD was increased in males, in Roman Catholics, in those reporting a history of major depression, social anxiety problems, and conduct disorder, or (in females only) a history of suicide attempt and childhood sexual abuse; but was decreased in those reporting Baptist, Methodist, or Orthodox religion, in those who reported weekly church attendance, and in university-educated males. After allowing for the effects of sociodemographic and psychiatric predictors, 47 % (95 % CI 28-55) of the residual variance in alcoholism risk was attributable to additive genetic effects, 0 % (95 % CI 0-14) to shared environmental factors, and 53 % (95 % CI 45-63) to non-shared environmental influences. Conclusions. Controlling for other risk factors, substantial residual heritability of AD was observed, suggesting that psychiatric and other risk factors play a minor role in the inheritance of AD.

Population pharmacokinetics of metformin in late pregnancy

The pharmacokinetic disposition of metformin in late pregnancy was studied together with the level of fetal exposure at birth. Blood samples were obtained in the third trimester of pregnancy from women with gestational diabetes or type 2 diabetes, 5 had a previous diagnosis of polycystic ovary syndrome. A cord blood sample also was obtained at the delivery of some of these women, and also at delivery of others who had been taking metformin during pregnancy but from whom no blood had been taken. Plasma metformin concentrations were assayed by a new, validated, reverse-phase HPLC method, A 2-compartment, extravascular maternal model with transplacental partitioning of drug to a fetal compartment was fitted to the data. Nonlinear mixed-effects modeling was performed in'NONMEM using FOCE with INTERACTION. Variability was estimated using logarithmic interindividual and additive residual variance models; the covariance between clearance and volume was modeled simultaneously. Mean (range) metformin concentrations in cord plasma and in maternal plasma were 0.81 (range, 0.1-2.6) mg/L and 1.2 (range, 0. 1-2.9) mg/L, respectively. Typical population values (interindividual variability, CV%) for allometrically scaled maternal clearance and volume of distribution were 28 L/h/70 kg (17.1%) and 190 L/70 ka (46.3%), giving a derived population-wide half-life of 5.1 hours. The placental partition coefficient for metformin was 1.07 (36.3%). Neither maternal age nor weight significantly influenced the pharmacokinetics. The variability (SD) of observed concentrations about model-predicted concentrations was 0.32 mg/L. The pharmacokinetics were similar to those in nonpregnant patients and, therefore, no dosage adjustment is warranted. Metformin readily crosses the placenta, exposing the fetus to concentrations approaching those in the maternal circulation. The sequelae to such exposure, ea, effects on neonatal obesity and insulin resistance, remain unknown.

Statnote 18: comparison of regression lines

In many circumstances, it may be of interest to discover whether two or more regression lines are the same. Regression lines may differ in three properties, viz., in residual variance, in slope, and in elevation; all of which can be tested using analysis of covariance. If there are no significant differences between regression lines, an investigator may which to combine the data from different studies and fit a single regression line to the whole of the data.

Wie lässt sich Klassenführungsexpertise messen? Überprüfung eines videobasierten Erhebungsinstruments für Lehrkräfte unter Anwendung der Generalisierbarkeitstheorie

Klassenführungsexpertise stellt ein wesentliches Merkmal der professionellen Kompetenz von Lehrkräften dar und geht mit positiven Wirkungen sowohl hinsichtlich der Qualität des Unterrichts als auch im Kontext sonderpädagogischer Förderung einher. Um kognitive Anforderungsdimensionen von Klassenführungsexpertise zu erfassen, wurde ein Testverfahren entwickelt, das anhand von 4 Videovignetten und 27 Items die Genauigkeit der Wahrnehmung (1), die holistische Wahrnehmung (2) und die Rechtfertigung einer Handlung (3) als situationsspezifische Eigenschaften von Klassenführungsexpertise misst. In der vorliegenden Generalisierbarkeitsstudie wurde unter Verwendung einer Stichprobe (n=188) von Lehramtsstudierenden, Referendaren und Referendarinnen sowie berufstätigen Lehrpersonen den Fragen nachgegangen, (a) wieviel Varianz auf die verschiedenen Facetten (Personen, Videos, Items) zurückzuführen ist sowie b) ob sich die Generalisierbarkeit der Befunde durch eine höhere Anzahl an Videovignetten verbessern lässt. Die Ergebnisse zeigen erwartungskonform, dass der Großteil der erklärbaren Varianz auf die Items (22%) zurückzuführen ist. Die Videovignetten (0.54%) bzw. die Interaktion der Videos mit den Personen (1.77%) erklären hingegen nur einen marginalen Varianzanteil. Es bleibt ein großer Anteil nicht aufzuklärender Residualvarianz (66%). Der Generalisierbarkeitskoeffizient liegt mit Ep2=.75 im zufriedenstellenden Bereich und lässt sich durch eine höhere Anzahl an Videos nur geringfügig steigern (Ep2=.84 bei 10 Videos). Die Ergebnisse weisen darauf hin, dass die gewählten Videovignetten eine repräsentative Auswahl an Unterrichtssituationen darstellen, eine höhere Anzahl an Videos aus ökonomischen Gründen jedoch nicht zu empfehlen ist. (DIPF/Orig.)

Modelos linear e não linear em análises genéticas para sobrevivência de crias de ovinos da raça Santa Inês.

Resumo: Registros de sobrevivência do nascimento ao desmame de 3846 crias de ovinos da raça Santa Inês foram analisados por modelos de reprodutor linear e não linear (modelo de limiar), para estimar componentes de variância e herdabilidade. Os modelos usados para sobrevivência, analisada como característica da cria, incluíram os efeitos fixos de sexo, da combinação tipo de nascimento-criação da cria e da idade da ovelha ao parto, efeito da covariável peso da cria ao nascer e efeitos aleatórios de reprodutor, da classe rebanho-ano-estação e do resíduo. Componentes de variância para o modelo linear foram estimados pelo método da máxima verossimilhança restrita (REML) e para o modelo não linear por uma aproximação da máxima verossimilhança marginal (MML), pelo programa CMMAT2. O coeficiente de herdabilidade (h2) estimado pelo modelo de limiar foi de 0,29, e pelo modelo linear, 0,14. A correlação de ordem de Spearman entre as capacidades de transmissão dos reprodutores, com base nos dois modelos foi de 0,96. As estimativas de h2 obtidas indicam a possibilidade de se obter, por seleção, ganho genético para sobrevivência. [Linear and nonlinear models in genetic analyses of lamb survival in the Santa Inês hair sheep breed]. Abstract: Records of 3,846 lambs survival from birth to weaning of Santa Inês hair sheep breed, were analyzed by linear and non linear sire models (threshold model) to estimate variance components and heritability (h2). The models that were used to analyze survival, considered in this study as a lamb trait, included the fixed effects of sex of the lamb, combination of type of birth-rearing of lamb, and age of ewe, birth weight of lamb as covariate, and random effects of sire, herd-year-season and residual. Variance components were obtained using restricted maximum likelihood (REML), in linear model and marginal maximum likelihood in threshold model through CMMAT2 program. Estimate of heritability (h2) obtained by threshold model was 0.29 and by linear model was 0.14. Rank correlation of Spearman, between sire solutions based on the two models was 0.96. The obtained estimates in this study indicate that it is possible to acquire genetic gain to survival by selection.