Variability in Holstein heifer heart-girth measurements and comparison of prediction equations for live weight

Measurement of heart-girth (chest circumference) is commonly used to estimate dairy heifer body weight from previously derived equations or tables. In this experiment, variability of heart-girth measurements as they are taken in the field was analyzed to determine the standard deviation within a group of 26 Holstein heifers of various ages weighing 42–590 kg. Standard deviations were 2.19 cm among 26 observers and 2.74 cm within any one observer. Repeatability between two heart-girth measurements by an individual observer on the same animal using a blind heart-girth tape was >0.99. Correlation coefficients between two measurements by different observers using blind measuring tapes on the same animal also were >0.99, with 99% of total differences due to observer and heifer, indicating very little random variation. A second part of this study was the validation of the most recently derived equation to calculate body weight from heart-girth. The equation was validated with data sets from universities across the United States and field data collected specifically for this study. Experimental and field data comprised of heart-girth and body weight measurements upheld the previously derived equation and support its continued use. These results allow more precise interpretation of heart-girth data collected from field studies with Holstein dairy heifers and provide more complete validation of existing body weight-prediction equations.     

Development of an enzyme-linked immunosorbent assay for Bordetella avium

A Bordetella avium enzyme-linked immunosorbent assay (ELISA) was developed to detect serum antibodies in 1-day-old poults, experimentally infected turkeys, and naturally infected turkeys. The optimized procedure included use of a suspension of whole bacteria coated onto plastic microtiter plates, a 1:200 serum dilution, a 1:3200 dilution of commercially available goat anti-turkey IgG (heavy and light chain) conjugated with horseradish peroxidase, and 0.04% orthophenylenediamine as substrate. A sample/negative (S/N) ratio method of analysis was used to estimate antibody titer from absorbance values. The regression equation used to estimate antibody titers was derived from the testing of naturally infected turkey sera. The equation was derived by plotting the log10 titer of the sera against the S/N ratio at a 1:200 serum dilution. The ELISA was an effective method for detecting antibody to B. avium, and the procedure should prove useful for laboratories equipped for high-volume ELISA testing.     

Mycoplasma meleagridis of turkeys: probability of eliminating egg-borne infection

An equation was developed that describes the probability of eliminating egg-borne Mycoplasma meleagridis (MM) of turkeys by egg treatment. Probability (P) of MM elimination was described in terms of four parameters: pretreatment prevalence of MM, alpha; treatment failure rate, beta; number of eggs treated, n; and hatching rate, h. The eradication equation, based on the Poisson probability distribution, was P(0) = e-n alpha beta h. Probabilities derived from 12 hypothetical MM-eradication situations showed that increasing the size of any or all of the parameters decreased the likelihood of eradication. Use of the predictive equation as a planning tool in a successful MM-eradication program is demonstrated.     

Accuracy of prediction of the liveweight of horses from body measurements

Fifty-three horses, all but two of them over two years of age and varying in type, sex and liveweight (230 to 707 kg) were weighed and seven different body measurements were recorded in duplicate by a single operator. The best overall prediction of liveweight using an equation with two variables was found to be: liveweight (kg) = (umbilical girth [cm])1.78 X (length of body from tuber ischii to elbow [cm]0.97/3011). This equation had an adjusted R2 value of 94.9 per cent and was derived from the pooled data, because differences of sex, type and weight did not significantly affect the relationship. The stable behaviour of the relationship was demonstrated by the fact that about 95 per cent of the residuals lay within +/- 53 kg, giving an average error of 4.7 per cent. The accuracy of prediction of the equation was better than the accuracy of four other established equations. A nomogram based on the equation is given.     

奶牛和肉牛日粮淀粉和葡萄糖的营养调控及其评定的建议

谷物饲料干物质中的淀粉含量多在50%以上,全株玉米青贮的淀粉含量亦有30%。牛的玉米日粮生淀粉消化率比熟淀粉低,但熟淀粉由于瘤胃消化率很高,所以瘤胃后的可消化淀粉量很低。生糖前体能量(瘤胃丙酸 肠可消化淀粉)能明显提高产奶量和乳蛋白率,但导致乳脂率下降。须对生糖前体能量进行评定和调节,以提高产奶效率。对真胃灌注不同梯度的葡萄糖或淀粉均显着地提高了Kf和体脂肪及体蛋白质沉织,因此我国肉牛饲养标准提出的Kf(%)=11.7645 55.756(IDOM/FNDF)仍适用,但可进一步增加IDOM中的淀粉调控。     

Recombinant LipL32 antigen-based single serum dilution ELISA for detection of canine leptospirosis

A recombinant antigen-based single serum dilution enzyme-linked immunosorbent assay (ELISA) was developed to measure the specific antibody activity in sera of dogs with leptospirosis. The recombinant antigen developed and used in the assay was specific for the pathogenic serovars of Leptospira. A linear relationship was found to exist between the predicted antibody titres at a single working dilution of 1:1000 and the corresponding observed serum titres as determined by the standard serial-dilution method. Regression analysis was used to determine a standard curve from which an equation can be derived that allows demonstration of the mentioned correlation. The equation was then used to convert the corrected absorbance readings of the single working dilution directly into the predicted ELISA antibody titres. The assay was proved to be sensitive, specific and accurate as compared to the standard microscopic agglutination test (MAT).     

Relationship between plasma creatinine concentration and glomerular filtration rate in dogs

Glomerula filtration rate (GFR), plasma creatinine concentration (CR), and plasma urea nitrogen concentration (BUN) were measured in 129 adult dogs with reduced renal mass. A preliminary examination of the relationship between CR and GFR was conducted, and the inverse model (GFR vs. 1/CR) was chosen for further evaluation. The slope of the regression of GFR on 1/CR which was computed from actual data was not statistically different from a theoretical regression line generated from the clearance equation.
Evaluation of subsets of the population revealed no significant difference between male ( n = 69) and female (n = 60) dogs on the slope of the regression equations. Diets differing in protein concentration (16% protein, n = 35: 21% protein, n = 75: 32% protein, n = 19) did not cause a significant difference in the slope of the regression equations.
The regression equation and the confidence intervals generated in this study may be used to predict a probable range of GFR values from CR in individual dogs. Such values may be useful in adjusting drug dosages in dogs with renal disease. However, since the derived equation did not differ significantly from the theoretical inverse relationship between GFR and CR, it remains to be established whether the equation is advantageous.     

Evaluation of 99mTc-diethylenetriaminepentaacetic acid nuclear imaging for quantitative determination of the glomerular filtration rate of dogs

The suitability of 99mTc-diethylenetriaminepentaacetic acid (99mTc-DTPA) as an agent to assess glomerular filtration rate (GFR) in dogs was evaluated. Glomerular filtration rates of 12 healthy dogs were determined on the basis of creatinine and/or inulin clearance. Glomerular filtration rates also were determined in 7 dogs after induction of acute renal failure by administration of amphotericin B. The healthy dogs and the amphotericin B-treated dogs were given 99mTc-DTPA (1 to 2 mCi) IV. The percentage of the 99mTc-DTPA dose in the kidneys (percentage dose) was determined, with background activity subtracted from total activity at 15-s intervals 0 to 6 minutes after 99mTc-DTPA infusion. Linear regression analyses (LRA) were performed to determine whether the percentage dose at various time intervals after injection correlated with GFR calculated on the basis of creatinine and inulin clearance data. One to 3 minutes after 99mTc-DTPA administration appeared to be the best period for analysis of the data. The percentage dose of 99mTc-DTPA (corrected for kidney depth differences) was determined and LRA against GFR were performed. The percentage dose correlated better with inulin clearance (r = 0.94) than with endogenous creatinine clearance (r = 0.83). Only inulin clearance correlations improved with kidney depth correction. The LRA was used to derive an equation that could be used to calculate GFR on the basis of the percentage dose. The equation derived from inulin regression was: GFR (milliliter/minute/kilogram of body weight) = 0.194 (depth-corrected percentage dose)--0.37; the equation derived from the creatinine regression was: GFR (milliliter/minute/kilogram) = 0.171 (depth-corrected percentage dose)-0.15.(ABSTRACT TRUNCATED AT 250 WORDS)     

In vivo prediction of internal fat weight in Scottish Blackface lambs, using computer tomography

From a calibration trial involving computer tomography (CT) scanning and dissection of 45 lambs, a prediction equation was derived to estimate total internal fat weight in Scottish Blackface lambs from measurements taken on cross‐sectional CT images. Using data from two cross‐sectional images (at the hip and loin) internal fat can be predicted with relatively high accuracy (adjusted R² = 62.2%, r = 0.79). The derived equation was then used to predict internal fat weights in a further 427 Scottish Blackface lambs from a separate trial. Phenotypic correlations were calculated between predicted internal fat weight and weights of total carcass fat, muscle and bone, predicted using previously derived equations. When considering absolute tissue weights, adjusted for fixed effects, internal fat showed the strongest positive correlation with carcass fat (0.58), followed by muscle (0.36), and then by bone (0.32). When tissue weights were adjusted for fixed effects and total carcass weight (so considering tissue weights relative to size), internal fat showed a lower correlation with carcass fat weight (0.36) and negative correlations with muscle (?0.35) and bone (?0.19). These results provide the basis for more complex studies of relationships (phenotypic and genetic) between internal fat in hill lambs and economically important traits, such as carcass composition and survival of lambs, and tissue levels in different depots in hill ewes.     

牦牛品种的AFLP分析及其遗传多样性研究

采用AFLP分子标记技术对麦洼牦牛、九龙牦牛、大通牦牛和天祝白牦牛进行了遗传多样性分析,结果表明:7个AFLP引物组合共获得156个片段,其中98个为多态性标记,标记多态频率为34.8%~54.65%,平均每对引物可获得17.57条带。九龙牦牛、麦洼牦牛、大通牦牛、天祝白牦牛的Shannon遗传多样性指数分别为0.268、0.251、0.160、0.130,九龙牦牛最大,麦洼牦牛次之,天祝白牦牛最小。用Rogers遗传距离公式分析得到4个牦牛品种间的遗传距离DR,天祝白牦牛与九龙牦牛遗传距离最大(0.028 2),天祝白牦牛与大通牦牛的距离最小(0.025 3)。根据DR值,将4个牦牛品种聚为两大类,九龙牦牛聚为一类,其它3个牦牛品种聚为一类。     

Relationship of glomerular filtration rate based on serum iodixanol clearance to IRIS staging in cats with chronic kidney disease

We examined the correlation between the glomerular filtration rate (GFR) estimated from an equation based on the serum iodixanol clearance technique and International Renal Interest Society (IRIS) stages of chronic kidney disease (CKD) in cats. The equation included the injection dose, sampling time, serum concentration and estimated volume of distribution (Vd) of the isotonic, nonionic, contrast medium iodixanol as a test tracer. The percent changes in the median basal GFR values calculated from the equation in CKD cats resembled those of IRIS stages 1–3. These data validate the association between the GFR derived from the simplified equation and IRIS stages based on the serum creatinine concentration in cats with CKD. They describe the GFR ranges determined using single-sample iodixanol clearance for healthy cats and cats with various IRIS stages of CKD.     

Evaluation of urea dilution as a technique for estimating body composition of beef steers in vivo: validation of published equations and comparison with chemical composition

Urea dilution equations for prediction of empty body water in live cattle, developed by three separate groups of investigators, were evaluated by comparing empty body water calculated by these equations with that measured chemically in 6-, 12- and 18-mo-old crossbred beef steers (n = 10, 9 and 9, respectively). Of four equations for prediction of percent empty body water, one derived from mixed-breeds of steers overestimated empty body water in the 6-mo-old steers by 7.59% (P less than .05). For the 12- and 18-mo-old steers, calculated and measured percent empty body water did not differ (P greater than .05). Of seven equations for calculation of empty body water volume, two derived from Angus steers with an without live weight in the equation, and one derived from a combination of Angus and mixed-breeds of steers overestimated empty body water (P less than .05) in the 6-mo-old steers. No differences (P greater than .05) between calculated and measured empty body water volume were observed for either the 12- or 18-mo-old steers. When calculated empty body water values were regressed against that measured directly, all regression slopes were not different from 1 (P greater than .05). Intercepts from regressions involving percent empty body water (four equations) were not different from 0. Three of the seven equations for calculation of empty body water volume, one derived from bulls and the others from Angus steers had intercept estimates not different (P greater than .05) from 0. Validity required that these regressions have slopes not different from 1 and intercepts not different from 0. Empty body water calculated from equations that combined live weight and urea space were more highly correlated with directly measured empty body water than that calculated from equations derived only from urea space. Urea space correlations with body composition of our steers also were improved when live weight was included with urea space in multiple regression models. Results of this study suggest that before using any prediction equation for calculating body composition of cattle in vivo, equations should be tested with a sub-sample of cattle from the population for which its use is intended.     

甘肃景泰灌区玉米收籽与收刈青贮临界适期的研究

研究了甘肃景泰灌区玉米灌浆期间籽粒增重和含水量的变化以及不同营养器官不同部位含水量的变化规律。结果表明，籽粒增重过程符合Ｌｏｃｉｓｔｉｃ曲线，籽粒含水量变化符合欠多项式；植株含水量变化随顺官和不同而异，其平均含水量变化地二次多项一普增重曲线方程、灌浆速度方程、植株含水量变化过程及其玉米秸杆青贮所需的适宜含水量进行综合分析，该地区玉米好籽、青贮临界收刈适期为吐丝后３７－４８ｄ。     

A generalized Michaelis-Menten equation for the analysis of growth

The functional form W = (W0Kc + Wf t(c)) /(Kc + t(c)), where W is body size at age t, W0 and Wf are the zero- and infinite-time values of W, respectively, and K and c are constants, is derived. This new generalized Michaelis-Menten-type equation provides a flexible model for animal growth capable of describing sigmoidal and diminishing returns behavior. The parameters of the nonlinear model are open to biological interpretation and can be used to calculate reliable estimates of growth traits, such as maximum or average postnatal growth rates. To evaluate the new model, the derived equation and standard growth functions such as the Gompertz and Richards were used to fit 83 growth data sets of different animal species (fish, mice, hamsters, rats, guinea pigs, rabbits, cats, dogs, broilers, turkeys, sheep, goats, pigs, horses, and cattle) with a large range in body size. A comparative study was carried out based on mathematical, statistical, and biological characteristics of the models. The statistical goodness-of-fit achieved with the new model was similar to that of Richards, and both were slightly superior to the Gompertz. The new model differed from the others with respect to some of the estimated growth traits, but there were highly significant correlation coefficients between estimates obtained with the different models, and the ranking of animals based on growth parameters computed with the new function agreed with the rankings computed by the other models. Therefore, the new model, with its variable inflection point, was able to adequately describe growth in a wide variety of animals, to fit a range of data showing sigmoidal growth patterns, and to provide satisfactory estimates of traits for quantifying the growth characteristics of each type of animal.     

Genotype and treatment biases in estimation of carcass lean of swine.

Carcasses of 181 barrows, representing five genotypes, 1) H x HD, 2) SYN, 3) HD x L[YD], 4) L x YD, and 5) Y x L (H = Hampshire, D = Duroc, SYN = synthetic terminal sire line, L = Landrace, and Y = Yorkshire), and two levels of ractopamine (RAC) treatment (0 and 20 ppm) were completely dissected and the data were used to examine genotype and treatment (RAC) biases in estimation of fat-standardized lean weight and to evaluate accuracies and precisions realized by use of equations based on variables derived from different technologies. Independent variables used to establish regression equations represented technologies of direct carcass measurements, optical probe data, TOBEC (total body electrical conductivity) readings, and dissected (DHMLN) and fat-standardized (FSHMLN) ham lean. Genotype bias existed when any equation from a single technology was used and was minimized by combining FSHMLN with one TOBEC reading, carcass length, and the probe measurement of 10th rib fat depth. Large RAC biases appeared when equations from direct carcass measurements or optical probe data were used and were minimized by an equation using either DHMLN or FSHMLN. A practical equation with relatively high R2 value and small genotype and RAC biases were developed by combining TOBEC readings with direct carcass measurements of 10th rib fat depth and warm carcass weight.     

Joint research on the precise determination of the energy and protein requirements of fattening pigs. 3. The energy requirement of hybrid swine

The energy requirement for hybrid pigs ((large white X land race pig) X line 150) in the live weight range between 35 and 120 kg is derived from 242 measurings of the total metabolism as the sum of energy requirement for maintenance and energy requirement for live weight gain. Energy requirement is estimated by means of the following equation: (Formula: see text). Energy maintenance requirement, energy content per 1 kg live weightgain in dependence of the daily gain and the derived energy requirement for growth and fattening are compared with corresponding results from investigations with pigs of the species large white and land race pig. Essential differences concerning parameters of energy metabolism determining the requirement could not be detected.     

Definition and determination of acetabular component orientation in cemented total hip arthroplasty

OBJECTIVE: To describe the spatial orientation of the cemented acetabular component in cemented total hip arthroplasty, based on a ventrodorsal and lateral radiographic projection of the pelvis. METHODS: Equations were derived by using trigonometric relationships that describe the radiographic rotation about the longitudinal pelvic axis (alpha), transverse pelvic axis (beta), acetabular inclination (phi), acetabular inclination corrected for longitudinal pelvic rotation, version (phiC), acetabular version (theta), acetabular version corrected for longitudinal pelvic rotation (thetaC), acetabular inclination corrected for transverse pelvic rotation (phi(beta)), and acetabular version corrected for transverse pelvic rotation (theta(beta)) RESULTS: Alpha was calculated by using the equation alpha = sin(-1) (x/y) where x is the transverse distance between the dorsal spinous processes and the center of the pubis on a ventrodorsal radiograph and y is the distance from the pubis to the dorsal aspect of the first coccygeal vertebra perpendicular to the long axis of the pelvis on a lateral radiograph. Phi was calculated from the long axis (LA) and short axis (SA) of the ellipse formed by the radiopaque acetabular marker ring by using the equation phi = sin(-1) (SA/LA). phiC was calculated by using the equation phiC = phi +/- (alpha - tan(-1) (tan alpha cos thetaC)). Theta was determined as previously described. ThetaC was calculated by using the equation thetaC = tan(-1) (tan theta cos alpha). Theta(beta) and theta(beta) were calculated with the equations phi(beta) = tan(-1) (tan theta cos beta) and theta(beta) = theta - tan(-1) (sin beta), respectively. Beta could not be accurately determined from ventrodorsal and lateral pelvic radiographs. CONCLUSIONS AND CLINICAL RELEVANCE: These techniques allow for more accurate postoperative radiographic assessment of acetabular component positioning. This information can then be used in retrospective or prospective analyses examining that effects of implant positioning on clinical outcome.     

Abnormal Hemostatic Profiles and Gastric Necrosis in Canine Gastric Dilatation-Volvulus

Hemostatic profiles (prothrombin time, activated partial thromboplastin time, fibrinogen concentration, fibrin degradation product concentration, platelet count, and antithrombin III activity) were acquired prospectively in 20 dogs with a diagnosis of gastric dilatation-volvulus. Eighteen dogs had abnormal results of one or more hemostatic test, including eight dogs that had hemostatic profiles consistent with a diagnosis of disseminated intravascular coagulation. During surgery, or at necropsy, the dogs' stomachs were evaluated for gross abnormalities, and lesions were graded subjectively as mild, moderate, or severe. Eight dogs had mild gastric lesions, five had moderate lesions, and seven had severe changes indicating gastric necrosis. Seventy percent (7/10) of the dogs with two to six abnormal hemostatic test results had gastric necrosis, whereas none of the 10 dogs with no or one abnormality had gastric necrosis (p < .001). A multiple linear regression equation, based on fibrin degradation product concentration, activated partial thromboplastin time, and antithrombin III activity was derived to predict gastric necrosis. This equation correctly identified gastric necrosis with 86% sensitivity, 100% specificity, 100% positive predictive value, and 93% negative predictive value.     

Automatic gravimetric calorimeter with simultaneous recording of physical activity for poultry

An automatic calorimeter, based on gravimetric principles, for studies on the energy metabolism of the fowl, with simultaneous recording of the physical activity, is described. In order to reduce errors in the determination of heat production to below 3% a three hour experimental period is necessary. The length of this period in comparison to that of the Pettenkofer system is discussed. The relation between heat production and physical activity shows a good fit in a linear regression equation, from which resting heat production is derived. Up to 25% of the total heat production is related to physical activity, mainly during the day-time.     

Mixture model equations for marker-assisted genetic evaluation

Marker‐assisted genetic evaluation needs to infer genotypes at quantitative trait loci (QTL) based on the information of linked markers. As the inference usually provides the probability distribution of QTL genotypes rather than a specific genotype, marker‐assisted genetic evaluation is characterized by the mixture model because of the uncertainty of QTL genotypes. It is, therefore, necessary to develop a statistical procedure useful for mixture model analyses. In this study, a set of mixture model equations was derived based on the normal mixture model and the EM algorithm for evaluating linear models with uncertain independent variables. The derived equations can be seen as an extension of Henderson's mixed model equations to mixture models and provide a general framework to deal with the issues of uncertain incidence matrices in linear models. The mixture model equations were applied to marker‐assisted genetic evaluation with different parameterizations of QTL effects. A sire‐QTL‐effect model and a founder‐QTL‐effect model were used to illustrate the application of the mixture model equations. The potential advantages of the mixture model equations for marker‐assisted genetic evaluation were discussed. The mixed‐effect mixture model equations are flexible in modelling QTL effects and show desirable properties in estimating QTL effects, compared with Henderson's mixed model equations.