IISSN 0704-3716

CANADIAN TRANSLATION OF FISHERIES AND AQUATIC SCIENCES

No. 4777

Understanding growth patterns by application of non-linear growthmodels to body measurements of female Japanese black cattle

,by

F. Mukai, Y. Wada, K. Namikawaand K. Tanase

Original Title: Kuroge washu meushi no taisokuteichi e no hisenkei hatsuikumoderu no atehame ni yoru hatsuiku yoso no haaku

From: Nippon Chikusan Gakkai-Ho 51: 247-255, 1980.

Translated by the Translation Bureau(RAY/PS)Multilingual Services Division

Department of the Secretary of State of Canada

I.

Department of Fisheries and OceansNorthwest Atlantic Fisheries Centre

St. John's, NFLD

' 1981

23 pages typescript

Into - En Translated from - Traduction de

'tjaPalleSe English

DATE OF PUBLICATION DATE DE PUBLICATION

Volume Year Année

Issue No. Numéro

2 4 51 1980

Publisher - Editeur

Japanese Society of Zoo-technical Science

Place of Publication Lieu de publication

Page Numbers In original Numéros des pages dans

l'original

247-254- Number of typed pages

Nombre de pages dactylographiées 24

Requesting Department Ministère-Client Notre dossier no

Fisheries and Oceans Translation Bureau No. 860927

Your Number Votre dossier no s .. ;. s..;

;7 • , ;

r 111dÉig Secretary Secrétariat 19` . of State d'État

MULTILINGUAL SERVICES DIVISION — DIVISION DES SERVICES MULTILINGUES

TRANSLATION BUREAU BUREAU DES TRADUCTIONS

LIBRARY IDENTIFICATION — FICHE SIGNALÉTIQUE

Author - Auteur

MUKAI Fumio, WADA Yasuhiko, NAMIKAWA Kiyoshi, TANASE Katsumi Title in English or French - Titre anglais ou français

Understanding Growth Patterns by Application of Non-Linear

Growth Models to Body Measurements of Female Japanese Black Cattle Title in foreign language (Transliterate foreign characters) Titre on langue étrangère (Transcrire en caractères romains)

Kuroge Washu Meushi no Taisokuteiài e no Hisenkei Hatsuiku

Moderu no Atehame ni yoru Hatsuiku Y8s8 no Haaku Reference in foreign language (Name of book or publication) in full, transliterate foreign characters. Référence en langue étrangère (Nom du livre ou publication), au complet, transcrire en caractères romains.

Nihon Chikusangakkai -H5

Reference in English or French - Référence en anglais ou français

Japanese Journal of Zootechnical Science

Branch or Division SIPB .. Direction ou Division

Translation (initials) Traducteur (initiales) RAY / ".2L;

Person requesting Demandé par — :3 1

Date of Request June 23, 1981 Date de la demande

(reçuest received Sept. 17, 1981)

* niternnte title : The fittinc of the nonlinear crowth models for describine rowti

patterns of body weieht and meaaurements in Japanese black female culve:i

•

SEC 5-111 (81/01)

TRANSLATION BUREAU BUREAU DES TRADUCTIONS

• [.;

e Secretary Secrétariat of State d'Ètat

MULTILINGUAL SERVICES DIVISION — DIVISION DES SERVICES MULTILINGUES

Client's No.—No du client Department — Ministère Division/Branch — Division/Direction City — Ville

Piulierieu and Oceanu 8ra OtLmul.

Bureau No.—Irdu bureau Language — Longue Translator (Initials) — Traducteur (Initiales)

860927 Japanese RAY / PS

UNDERSTANDING GROWTH PATTERNS BY APPLICATION OF NO INEAR

GROWTH MODELS TO BODY MEASUREMENTS OF FEMALE JAPANESE BLACK

CATTUE

MUKAI Fumio, WADA Yasuhiko, NAMIKAWA Kiyoshi and

TANASE Katsumi *

Kyoto University Faculty of Agriculture, Kyoto 606

*Gifu Prefectural Breeding Stock Farm, Kiyomi-mura,

Gifu Prefecture 506-01

(Rec'd. 30 .July 1979)

ABSTRACT

For the purpose of obtaining basic data to grasp growth

patterns of female Japanese Black cattle in simple paramet-

ers, the Brody, Logistic, Gompertz, von Bertalanffy and

Richards growth models were applied to body weight and to n.

other biometric valucs measured over a period of time after Eke_

weaning of 97 breed cows in three groups supplied to the

Gifu Prefectural Breeding Stock Farm beginning in 1968. We ,(L- Lo

determine the optimum model ) and an examination was

SEC 5-25T (Rev. 6/78)

2

made of source district differences among the parameters

estimated. With the exception of Richards, the number of

fitted indivïduals in all models was 80 (82%) or more for

body weight, body height, chest girth, chest depth, croup

length and hip width, and 50 (52%) or below for body length,

chest width, pin bone width, and cannon circumference. Since

the figure for chest width was particularly low, it was

excluded from subsequent analyses. In other words, the

numbers of fitted individuals varied more strikingly between the.

body measurements than among models. When degree of fit is

observed in terms of coefficients of determination, the fig-

ures were 90% or higher except for pin bone width and cannon

circumference. For residual mean squares, the number of

fitted individuals was large .for body weight, chest girth,

chest depth, hip width, etc., and as important biometric figures.

Logistic had the smallest. Negative coefficients were observed

for correlation between parameters for all items measured and

all models among the different mature sizes and maturing

rates. The coefficients of correlation among the parameters

corresponding to each of the models was extremely high, and

the parameters of all models were assumed to reflect the

same growth phenomena. Based on such facts, the application

of Logistic was found more suitable for biometrics of female

cattle for which growth records only after weaning were avail-

_trt.tmlatorle note : literally : ucontribution rabu"; ague herealter

3

able. An examination of regional differences in the paramet-

ersEstimated from Logistic showed significant differences in

mature size for croup length, hip width and thurl width, and in

maturing rate, aside from body length and thurl width. This

suggests the existence of pronounced regional differences

in the growth patterns of biometric figures.

The selection of beef cattle is based on weight at so

many months of age or the rate of growth within a certain

period. A positive hereditary correlation has been observed l) at birth,

between weight and growthvat weaning and at the age of 12

months. This is thought to be an inevitable result of the

increasing size of breeding females. The increasing demand

for the raising of breeding females, and.the fast, efficient

fattening of beef cattle are at cross purposes. In this

connection there has been some discussion2 ' 3) on the optimum

size for females from the standpoint of production efficiency

and attempts have been made to optimize the growth pattern

up to maturity through selection. 4,5)

The evaluation of proper size and growth of beef cattle

depends on comparisons of what are presented as normal

growth figures for the various breeds, but as a precondition

for making effective use of these specifications, the

_growth patterns must be of the same form for all individual

animals. It is evident, however, that striking variations

4

occur in the growth patterrs of individual beef cattle in the

period between birth and maturity. It follows that a quan-

titative grasp of the dynamic processes observed over time in

individual growing beef cattle is important. In the past,

because of the difficulty in collecting data and computational

limitations, research on growth has centred on cross-sectional

average;•growth. Figures were obtained from the observation

of large numbers of animals at different stages of growth,

which were then compiled and treated as lifetime growth.

Body weight was the prime focus of investigation. Few longi-

tudinal studies, i.e., examinations of individual growth,

were made, and problems remained concerning our grasp of

variables in that attribute of living thing called growth.

There was some attention given in actual practice to

the size of the hindquarters of the females as related to

difficulties in parturition and it was reported6'7) that the

development pattern of the hindquarters varied with different

breeds.

It was important, from this standpoint, to have a fun-

damental report on the growth pattern of Japanese Black

cattle in terms of individual growth, but in view of the

production system in Japan, growth records are often limited

to the period after weaning, or when the animal enters the

calf market, and the lack of data representing the first

stages has an effect on the varieties, etc., for suitable

p. x11;

5

models. In consideration of these conditions, these studies

applied a number of non linear growth models to growth records

of measurements taken after weaning to try to find a suitable

model. By looking at regional differences in estimated para-

meters, a further treatment has been made of their effective-

ness as guidelines expressing growth patterns.

MATERIALS AND METHODS

WC re

Ninety-seven head of female Japanese Blacks, v supplied for

breeding at the Gifu Prefectural Breeding Stock Farm. Measure-

ments of body weight, body height, withers height, body length,

chest girth, chest depth, chest width, croup length, hip

width, thurl width, pin bone width, and cannon circumference

were made and growth was recorded at about one-month inter-

vals.

Groups of females

were bro4ght in from Gifu in March and November of 1968, from

Okayama in July of the same year, and Tottori in the same

November. The number of animais and the measurement conditions

are as shown in Table 1. The Tottori females were aged 7.7

months at the startor measurements, significantly younger

than those from the other prefectures.

These females were raised in groups for experiments and

-tests on mass raising of breeding cattle. Groups of 25 were

raised in open barns and all animals were dehorned to prevent

4

6

a, b:

%nhlr 1 . The outltno of mat 'rials.

DisU•ictNo. of No. of Age of munths

anintals records Initial Ftnai l'criou

tiilu . 3.•., ! .311 10. . t . 1.5" :,U. t> ^ . •Ih •k). t• . ir.

Tollttri i ! . •1•1 %. .. :' l". <,n .11.

Okayama ;f, ..c+.42 IG.ï .21' hI.1 t..64 40.v .c,•:

Total ',; . 1 . ^ . .^.•i Q. •1 ! . 12 N"). •t ^ .07 •t 1. t' t . : n

Ntctlns with dlfft•trnt sulmrMripts are s:il;nilic:lnt ^ diffrrcnt tf'

Table L'. Equationa fnr lit•e g rowth models :,,u: derived t^.,.,.

\In(lcl I?^luatutn,a Y,-

0. I1Ci).

Mal tire Rate of Intlcctionsize nuiturinl; point

Kicltnl, A . I. . lit. ,,) ,1 A I,

a: Y. ^Ir.r at cltit• t. A. It, k and h! are littc,l parantctcrs.

damage from fighting. Uniform feed intake is controlled by

linked stanchions during feeding. Under a feeding regime

averaged over a period of 11 years, they were given 16 kg

silage and 2 kg rice straw per head per year as rough feed.

As concentrated fodder, they were given 2 kg in the summer

and 3 kg in winter of ordinary commercial mixed fodder.

Grazing was limited to approximately 50 days in the summer.

The five nonl inear growth model equations of Brody,

"Logistic, Gompertzi, von Bertalanffy and Richards were used

It

(Table 2). These are widely used for increases in bio-

logical body measurements and growth models. Size is expres-

sed in each model as a function of time t. When A ra te- oC

(mature size). And k is thevinstantaneous increase in

size, or a function of the spccd of increase with respect

to mature size. This is generally taken to be the rate of

maturing. B is the constant of integration and is the

coefficient determined by Y. at the point where t=0. Our

samples, however, included records for animais only after

the time of weaning, so the biological significance is

shaky. M (form parameter) is affected by the position of by

the point of inflection andvthe size at that point in time,

and is thus determined by the form of the curve. Hartley's 9)

modified Gauss-Newton iteration was appliedlo the biometric

values for each animal to investigate the suitability of

each of the models. When this was done, the initial value

established in order to obtain an iteration solution affects

the iterative frequency and the estimated values of the

parameters, so Wa1dford10) computed initial values using a

determined difference graphic method as a means of estimating

the limit value A from growth curves based on data not

containing the mature size. As iteration solutions for

A, B, k, and Id, the pooling of parameters giving the smallest 80.

residual square sum in 20 iterations was used. Since the

average iteration frequency was in the 17 to 19 range,

Table 3.

• • •

Number of fitted size •age data in 97 cows for growth model,

von Measurement Brady Log ist ic Gompertz Bertalanffy

Body weight 511). 98)' 9b( )8', 9(..i )9, ....I 99)

Withers height 8P. 134) 82( 8. ) 8 ..r ( ' . I 9:. 9 )

}lip height b8 ( (A) 88( ti n , :,, . ,,( 78)

Body lengt 11 • :.( ..(-.1 • 3( 44 • a:.1 ?hi (14, ht.)

Chest girth 97% )(T ) 97 (ICK.1 97(100) ''.'t li,ro

Chetil tIvi)th 94., 'a) 94( 9','' 9).;. 9;.) .r:d. 98 r

Ches1 with 1r : ( :.) 12( 1: . ) .i( r 1.:( 1.1

CI oup length 8» 'Or fe.( 8 H i( 87) ))« 9.))

11 ip wi(11 li 97( (VA 97(10(q '.',-( 1 ) )) 'r7( tutu

Thud whit h 711. 7:r Th( 77, (dig 7o i Ul t 84 )

l'in bone width aL., «di i *.%24 d.i', '..( .11)

Cannon circumference 2dt 2.i, -2n( 27. .:1( ,:el .7( :1?-31

a: Value in parent heses is fraction of fit ted animals Mi.

24 ))

there was no great difference between the models and the

biometric values. Model selection was based on the

number of fitted animals, goodness of fit, and the cor-

relation betweeniarameters in the model. The difference in

parameters for the various prefectures was treated as a

factor causing regression to differences in age at the

time of initial measurement, and Harvey's Least-Squares VarlahLe. 1) Analysisl method was used. Calculations were made with

-Kyoto University Large Computer Centre's FACOM M-190.

8

9

RESULTS AND DISCUSSION

Fitted individual values for models and biometric values

are as shown in'Table 3. Richards has no fit at any area wa›

measured, and veliminated from subsequent analysis.

In Richards, the number of parameters (M) affecting the

point of inflection is greater than in other models, which

makes convergence difficult, 12) and usually limits must

be placed on the parameters (Bel, OeMe6). This naturally

makes the conditions required for measured values stringent

as well, and not only the quantity, but the quality of the

measurement -- how much of the growth range does the meas-

urement cover? -- become problematic as a result. Thus,

the main reason the sample cattle in this study were not

fitted for Richards appears to be that records were lacking

for initial growth.

For body weight, body height, chest girth, chest depth,

croup length, hip width, fitting was made for 80 head (82%)

in each model, but the number of individuals fitted for body

weight, chest width, pin bone width and cannon circumference

was small. The number was particularly small for chest

width, which is eliminated from further analysis. Of the

models, von Bertalanffy tended to show the greatest number

of fitted individuals, and Gompertz, the smallest. On the

other hand, there were conspicuous differences in the bio-

metric figures. The causes were, firstly, that the measure-

10ment error varied depending on the place measured, and

6rtWcc-visecondly, there was differential rowth v the different

places measured. Even when measurements were made at

identical monthly intervals, the growth stage varied

from place to place, so the asymptotic lines or points

of inflection hypothesized in this model were not met.

Moreover, another cause of the general impossibility of

fitting was that, as shown in Table 5, there was a rather

high correlation among A, B, and k, producing multicolline-

arity in the variance and covariance for the purpose of ob-num6cr oL

taining least squares solutions and thevmatrix ranks

dropped.

Next, the residual mean squares and coefficients of

determination showing the portion accounted for by the sumsto bbe,.

of the squares due to the model, i.e. "" regression thrvuyhc,ut all

variations, were calculated to show the degree of fitting.

There is an error correlation between measurement values

at contiguous points in time in the growth process, which is

generally regarded as insufficient in determining the

goodness of fit.13) Nonetheless, when the measured values

for each individual and the values estimated from the model

are plotted and checked for systematic error, Logistic'sin sy>temati.: orror.

is smallest " The coefficient of determination was ob-

_served to be decidedly lower in models or measured areas

where systematic error arose. Based on this observation, it

1 1

11. • 411111 1i"I • Ill11 jet

7'able 4. Mean for coefficients of determination and average residual mean squares' for growth models*.

Measurement Brody Logistic Gompertz Ber vtaolial nffy

Body weight 0. 9Ib 0.93' 0.921e O. 92b

559.48 434.22 488.05 509. Fi•1

Withers height 0. 9h 0.95 0.95 0. 91

82* I. 78 I. 74 2. ():1

Hip height 0.93 0.93 0.93 0.92

1.95 1.91 1. 89 2. 01 . -

Body length 0.9I 0.92v 0,92b 0.90'

9.64 8.94 8. 74 9.81

Chest girth 0.91 0.92 0.91

ZO. 65 18.93 1 ,,. 74 .".0...)4

Chest depth 0.92 0.93 0.92 0.92

107 1.89 1.95 101

Croup length 0.92 0.94 0. 94

1.08 0.8ó 0.84 O. 9,.••

flip width 0.96 • 0.96 0.96 • O. 96

1.02 0.91 0.96 u. 98

Tlitirl width 0.90 0.91 0.92 0.91

0.94 0.86 0.83

l'in hone width 0.88 0.86 0.90 tS/

0.95 1. 16 u. 92 %).

Cannon circumference 0. 89 0.88 0.90 C. tia

0. 109 0. 110 0. 109 U. 0)8 • -•

The upper and lower values within each measurement show the coefficients of determination and the average residual mean squares respectively. a: Computed lw poolinjz squared deviations of each individual's size-age observations from predicted values. i.e.. where p is the number of parameters fitted, N is the

Nt. n's Ys.. 2/S' (t) - 13 )

1 1 number of animals and t k the number of sizes fur the j th. aitunal. h, e: \leans within a column with different superscripts are signilleant ly dilferent

1 .1 .: 0.05.

M L4111 1 'd 1 0 Ili: (1. 11M

Table 5. Residual correlations among growth parameters (rom four models'.

Brody (1) Logistic 1 2) Gumpertz (3) von Bertalanffy (4)

A 14 k A 14 k A l k A 14 k

• . 7(' • 9i - . 2:• • . 6t . . 39 - . . 9% . 611

.46 • .:.1b 4 I' 't•

• tt . • Y-I •.i/i .1,; ■

A 1.t.' . 34 •9`.; • . 90 • . 41

• 78 . • 30 .97 . 61 - .30 0, . 68

k 37 .8o 1.00 -.38 .83 -.38 .88 .99 -.60 . 9 I .97

A 1.00 • . 76 .37 1.00 --. 24 -.36 40 * .e-. 61 1.00 -. 4 ■; -.62

-. 26 1.00 -.28 1.00 . 84 . .8.: 1.00 .W

k 1. 00 .31) . 8! 1.00 -.36 .83 . o$ • 1.00

A 1.00 3.8 • -.44 .M

• .. 1.( .t•s - I .88 - • 1.00 .8. 7e .84

k •• • :;8 . bI , 1. (X ) . 38 • I. 00 • 37 • 83 i. 00 .37 . 8$

a: Coefficients above the diagonal represent for weight, and below for withers height which are calculated after adjustment for district and in age effects.

was thought that a certain magnitude of systematic error is

reflected vthe coefficient of determination. Because of

the need to compare the goodness of fit from polynomials

as done in the past, Table 4 shows average coefficients of

determination for the different models. Aside from pin bone

width and cannon circumference, a coefficient of determina-

tion of 90% or more was obtained for all measured items

12

A

I. Il

k

1.

13

even with the models. When the models were compared, a

significant difference was found in body weight and body

length, and Logistic and Gompertz were slightly better than

the others. A comparison of these with the coefficients

of determination for the growth curves by orthogonal poly-

nomial equations seen in average growth in Fukuhara et al14)

shows them slightly lower. In general, in average growth

individual variations due to environment or physiological

conditions cancelled each other out and the coefficient J S tonsr àred to 5r3cluà eta-

of determination was found to be higher ' individual

growth. Thus, it was found possible to

grasp individual variations only in terms of individual

growth, and considering the amount of information obtain-

able from the parameters, the coefficients of determina-

tion obtained seem sufficient.

Moreover, in order to examine in detail a comparison

of tic. the residual mean squares advocated

by Brown et al 12) were computed (Table 4). The number of

individuals fitted for body weight, chest girth, chest

depth, hip width, etc., was large, and for those biometric

figures regarded as important in the growth of beef cattle.

Logistic's residual mean squares were lower and exhibited

', .

^•••, ;. 't:^ LŸ t .•, . , ,^ , .^^(•• ^.7^Î i^C.:iI. rr^t)

:,'^ w:, . r . .!i

lli:V)71)..,.,

Tul,/r a. 1,ray; .+lu:urs mt•ans fur mctturr scizrr rate of mattn'ing stntlmont lis ul age at 9t1':;, tnaturity froul Logistic muclcl.

Mt•.ISUrcment

Iicxly wci);Ilt

1t'itBcrti ht•iy;ht

Thurl %vidtlt

l'in Iloilo wi(ItIj

Cannon circumference

District \o• A k ll. S1A`

G` ü1 427.7 .148' ... ^6.437.3 112" 3U.46

() •136.6 .174" 2;i.1'

(: 7.. I::•1.0 lUl" Ih.l' 3 125. I . 1()(J- 14.8

() 17 125.3 .118, 14. y

123. :11 .I'!.'l' i...:lIt 12•1.2 • 124'

() I. 124.3 . 16U+'

G Ic. 146.4 Uy7 19.tr: :.t. 143. 3 . I U6 - '+, i0 ï 147.8 (K)Y 17.U

G 18•I... 127' It, 1"

1 IA::.+) I

U 20 183. I . It,7''

G vo. r,

1 07.0

O 11 67..+ 1•iJ^ lt.,•r

G , . .^1.O•

lUl'' I ,() : :,(1.. .I:i;r

(i i'/. .1Q:•'^1^ :, I . t,'r , + ^•,

() l :,l)....,, I:'.•l' J.I.t'

(i 1231 i:. 44.01 . 10.', ::l'. 8•,

() 16 4:,.4" .12J 18.0'

G 14 27.7 • 134' 19. t.+I• +6 29.4 098° 4() 28.4 .IS:' :4.8

U

(: '1 I b. y . 141' I•I.',T •:^ 16.0 , I11^ 1n.(,

16.4 .110" 1.1,•,

a•illtin row with cliffcri'nt suprrscripts nre si^;nitic.t:ulvdiffcrcnl l' Il.ti,,. CI: Months of aKr at JIl9„ nuuurit)'• r(^,'l',Urrprcticnt (;ifu, 'l'olturi and Okayurn. ► r:spccti^rl).

14

It

25i.'.

15

superior fitting. Fitting was also observed to be excel-

lent in both the Gompertz and Logistic models for body

height, body length, croup length, and thurl width.

On the other hand, von Bertalanffy's residual mean squares,

which fitted many individuals, were larger. Regarding the

body weights of Hereford and Brahman hybrids, and Jerseys

from birth to selection time, Brown et al 12) made comparisons p..1 1; 1

beiween models similar to those in this report and reported

Logistic's residual mean squares to be the largest. On

the other hand, Mukai et al15) with post-weaning records on

castrated Japanese Black fatting cattle only,found that

Logistic showed excellent fitting, as in this report.

Differences in breed must be considered in connection with it

this kind of disparity an4fmay'be that the measurement range

for the sample animals had no small effect on a model's

goodness of fit. Differences in each of the models occurred ihwevcr, our results a e Ye‘'bOi.C.. t411 e ro 11«•"'t

at the position ottheir points of inflection. v Uutmodels

such as Logistic and Gompertz tended to show better

fitting the later the position of the point of inflection.

It ma y also be that at the age of initial measurement for

our sample animals, the true points of inflection, other

than for body weight, may already have been passed. Thus, the

points of inflection were extrapolated from the models and

- it was hypothesized that Logistic, with the values close

16

to those at the time of initial measurement, i.e., with

the point of inflection at the latest point in time, gave

the better fitting.

The residual correlations among the estimated para-

meters of each model were computed. Fig. 5 shows the re-

. sults for body weight and body height. A positive correla-1n4 a negaL'ive. ohr- be.twctn thc,ir_ at,d. A

tion was found between k and Bvamong the parameters in the

respective models. The relationship

between A and k is especially important for beef cattle.

This indicates that fast-growing cattle have a smaller

mature size. This relationship is in agreement with many

reports12,16,17^ concerning body weight in non-Japanese

breeds.

The models used in these studies were evolved from

different theoretical frameworks, each with its own mature

sizes and rates of maturing. The selection of the optimum

ought to be predicated on the models' parameters' having

the same significance and must be verified using identical

samples for interrelationships of models. Correlations be-

tween A-A, B-B, and k-k for each of the models were O.t37

w^,enor higher for body weight and 1.0 for body height. Evenvthe

correlations between models of A, B, and k were found, the

overall tendency was the same as within the models themselves.

1

These relationships were similar to those for other bio-

metric figures* . In view of this fact, the parameters of

all models were asume.c.4 to reflect roughly the saine growth

phenomena.

A comprehensive evaluation was made of the number of

individuals, the goodness of fit, and their correlative

relations and the Logistic model was found suitable for

application to females for which initial growth records

were lacking as in these sample animals.

So, in order to see whether or not Logistic's para-

meters obtained in this fashion were valid indicators for the

characterization of the growth patterns of individual herds,

an inquiry was made into A, k, and the influence of source

district on the animals at an age equivalent to 90%

maturity.

The reason the source district is mentioned here is

that when the sires and maternal grandsires of the females were eAarbibNet

they were classified as "Hyogo" strain from Gifu prefecture,

"Tottori" and "Okayama" strains from the two prefectlires of

the same names, and the historical growth processes were s. ) bhey w c re. estimated. to have_

considered for herds from each prefecture. ‘' different

genetic structures.

58 -

50

42

34

26

18

20

16 32 48 64 A e in months

16 32 48 64 A e in months

28 7

C. HIP WIDT11(em)

400

320 I--

I.

240 L.

12 16 32 48 64

Age in mnnths

„J.). T1111111.. WIDT11Ien 45

41

37

33

29

25

52

44

/./ 'Id

36

/•

18

4go L.. A. 1101)1' wt.:Harr kg' 60 _ II. CHOUP 1..1.3%.IGT11.em‘

lot 1 i L I t L__1 _ 21 __,....à ..1 .1 • 1

0 16 32 48 64 0 16 32 48 64

Age in months Age in month!.

Fig. 1. Mean growth curves predicted (rom Logistic model.

Gifu; Okayama; • -Tottori:

253

19

At the saine time, with respect to influences regres-

sive to the age of the initial measurements, A was sig-

nificant for body length, croup length and hip width,

and the superscripts drthe bias regression coefficients are

positive only for hip width. Also, k was found significant

for all parts measured, and the bias regression coefficients

were positive except for chest depth and thurl width. This

indicates that the rate of maturing may be estimated higher,

the more advanced the age of initial measurement. At a

90% mature age, the superscript changes sign, but the saine

phenomenon is observed as with k. However, the age of ini-

tial measurement was significantly younger for Tottori

cattle and the effects of the source district were found

to be partially confounding. Thus, further investigation

is required on the effects of differences in initial measure-

ment age on estimated parameter values. At the saine, time,

this also indicates that the effects of initial measurement

age must be taken into account in interpreting differences

between source districts.

Least square averages for A, k and age in months at

90% maturity are shown in Fig. 6 for each source district.

The estimated maturity in each case was within the approp-

riate range compared with normal growth of grazing females

as indicated by Fukuhara et al. 14) A significant difference

p. 2,53

20

(P 0.05) was found in A for measured items in the hindquar-

ters, such as the croup length, hip width, thurl width,

etc., and the animals from Gifu, chiefly "Hyogo" strain

had the smallest hindquarters. There was a significant

difference (P 0.05) in all biometric values for k except

for body length and thurl width. Overall, maturation was

fastest in the orders Okayama, Gifu, Tottori. The age in

months at 90% maturity was youngest in the orders Okayama,

Gifu , Tottori. The trend was similar to the rate of maturing.

A breakdown by measured item shows maturity occurring at a

younger monthly age in withers height, body height, cannon

circumference, with intermediate maturation in croup length,

chest depth, chest girth, thurl width, and pin . bone width,

and slower in hip width and body weight. Kumasaki et all8)

found that the age at which each area reached 90% maturity was

approximately 26 months. In this report it was 22 months

for animals from Okayama, 24 months for cattle from Gifu

prefecture, 27 months for those from Tottori -- so that

cattle from Okayama matured earliest overall. The relation-

ships among such characteristics and the fertility or meat-

producing ability are of interest. A graphic presentation

of the average growth curves by district of origin based

least squares means of parameters for body weight, croup

21

length, hip width and thurl width is given in Fig. 1.

Breed differences in body weight growth patterns were observed

by Brown et al, 12) Joandet and Cartwright, 19) and Matsukawa

et al. 20) Their average growth curves indicated that there

were differences among source districts thought to derive

from differences in genetic structure with regard to not

only body weight but other morphological measurements

as well. The growth patterns of female cattle from Okayama showed an overall fast rate of maturing and Lhe. mature size

was also smaller. This demonstrates a format at variance

with the pattern anticipated on the basis of correlations

in parameters, that is, with relationships where the mature

si was smaller for animals with a faster rate of maturing.

Thus, it may be assumed that desirable growth patterns arc

achievable through selection and crossbreeding. Brown et

al 12) observed similar phenomena in Hereford and Brahman

hybrids and reported the possibility of detecting hèterosis

in the rate of maturing. Meanwhile, causes for the growth

pattern peculiar to cattle from Tottori may be that, not

only were there differences in genetic structure as described

above, but also that the animals were supplied for obser-

vation at an earlier age than those from other prefectures,

and hence reacted sharply to environmental differences.

-Moreover, from May through October of 1969, i.e., before

first parturition, they were allowed to graze on artificial

.11•■ . . . • . .F.rr.M.re-,,••••••••■••- . •••■.•ney1■••••••••

REFERENCES

i\Ih.tl^l R ünll1) tta1NKN, J. y.. Il. à'. (,'i.AuK. N. M.

J. J. L1RICK, J. Antin. S ►:i., 23. 711 716. 196•1.

Z 1 1tuRRlti, C. A. and J. W. WILTuY, (:un. J. Anim.

tit i., 56: 613 647. 1976.3) MuRRIt+, C. A. and J. W. W ► LIUN, Anim. llrcud.

Abstr., 45: 139 153. 1977.

4) FITZHUatt, H. A., Jr.. Texas. Agr. Exp. Sta.

l'rog. Kep" 3121., 1972.

5) FlrxnucH, Il. A., Jr., J. Anim. 5ci., 42: 1036

1051. 1976.6) I..\tiTER, D. B., J. Anim. Sci., 36: 493 503.

1974.7) 1th:L1.OW, K. A., R. B. (,InSPN, 1). C. ANDERSON and

R. E. SHORT, J. Anim. Sci„ 33: 455-457. 1971.

8) NEVII.LF., W.15., Jr., B.G.1`11:LLINIX, Jr., J. 11.

SMIrH and W. C. McCoRMtcK, J. Anim. Sci., 47:

11)Ii0-10823. 1978.9) ) I\RTLEY, k-1. 0., Technomeirlcs, 3: 269 280.

1961.

10) WA{.DFORD, L., Hiol. Bull., 90: 141-147. 1946.

11) 1 tARYEY, W. R., Least•Squares Analysis of Data

with Uneyuul Subclass Numixors. AKS20•8.

U. S. ll. A. 196u. ,12) pti(jwx, J. L, 11. A. I*'IrxHUaH, Jr. and T. C.

.I>,.RTWRIG1iT, J. Anim. Sci., 42: ii10 818. 1976

13) I,R,ZZLE, J. 1S. and 1). M. ALI.EN, 131ometrH:s, 25:

337.-381. 1969. '

114, +ISIl,t fG - • ^1•^lq^l i, • iP4. 'lllxll^^^l1`Ii, 820.

1.50. 1973.15) ^iqll^lC11@ • f'r.^.^,^.% •^iNl i^), tltSrf I^tIP4 Kt^G

► '' 77: 14-14.. 1977.

16) (iRUwN, J. E.,' C. J. BRUWN and W.T. IiUTrti, J.

Anim. Sei., 34: 525 537. 1972.

171 I^InLLt:Rt+o Loi-t•i de ToRRr•. and IiuunY J. t:AN-

KIN, J. Anim. 5ci., 46: 604•b13. 1978.

18) •if[ • 11111 •^^Ih{iiil'^l.73 108. 1955.

19) JuANDh:r, U. li. and T. G. CARrwRIwltT, J. Amin.

:;Ci., 29: 862 ëliti. 1969.20) 1 ;1I1 il: • 1119+r ^^;i • fi ; ; r^ • ^,^Fsil^ hllys • ++

Jt, I 1^;r,^. JK, 30. 95 99. 1979.211 LAItFENTER, J. r1., Jr., U. A. l'IriHUGH, Jr., J.

E. [iROwN and E. K. CROCCH, Texas. Agr. Exp.

titü. l'roK. Rej). 2975., 1971.

22) \1uNrKRlu, 1.. S. und 1). S. l'u:o1^h:R. :1nln+.

l'rotl., 8: 179 192. 19litl.

24

.I

22

pasture. All these conditions inhibited early growth and

are thought tQ be reflected in the parameters.

Differences in mature size and maturing rit-e- of

the female cattle are related to a large extent to the amountwl+icit .tmou»b TepYrsF¢nfs a 19tge, pCoposEion oL ti+t proâactiurl toSEs ol talve

of fodder required for growth and sustenance: Geneticallybvdy-6wilding

ri cfi n1

speaking, the - capa.&y and maturation rate of later genera-

tions are considered to be influenced by the feeding effec-

tiveness and carcass composition of the fattening cattle.

Thus, these results suggest that when cattle are compared

in terms of both breed and different source districts, there

is a necessity to base onesoli ovi L^a vnaçurin5 ratt vs.con

lnaiuriny site. rather than merelyva given age or body weight.

Carpenter et a121) have reported that for animals with

a fast maturing rate, intervals between parturitions are shorter

and the lifetime number of wcancd calves is larger, while

the body weightuat weaning of calves from cattle with larger

body weight at maturing are greater and the number of product-

ive animals was smaller. Moreover, a connection was found

between the age at the point of inflection and sexual matu-

rity as regards body weight.22) Therefore, in the future

biometric data must be regarded not simply as grourth indices,

but as information usable in evaluating the most efficient

growth pattern for breeding females in terms of the inter-

( .7,

It

relationships of mature age, rate-of maturing, percentage

23

of maturing animals, point of inflection, etc., and calf

productivity:as well as growth in subsequent generations

of cattle.

Based on the above results, biometric records o£ Jap-

anese cattle in the initial growth period are often lacking

because of the make-up of the calf market and thus Logistic's

model seems applicable to this kind of data. Furthermore,

by fitting a growth model for individual growth, a huge

number of measurements at each stage of growth may be concentrated

into a small number of parameters and it was found to be

possible to obtain important data on figures characterizing

growth.

In closing, this research was assisted in part by funds

for scientific research from the Ministry of Education.

REFERENCES (JAPANESE TITLES)

14) Fukuhara, R., T. Obata, Y. Kiharab Chkoku N8-Shi-H8

(Chugoku Agricultural Testing Station Bulletin), B20:

1-50, 1973

15) Mukai, F., Y. Sasaki, K. Namikawal Nichi-Chiku-Kai Kansai

Shibu-H8 (Jap. J. of Zootechnical Sel., Kansai Branch

Report) 77: 14-14, 1977

18) Kumazaki, K., E. Tanaka, Y. Kihara, Cheigoku N8-Shi-H5

(Chugoku Agricultural Testing Station Bulletin), B4

73-108, 1955

20) Matsukawa, T., H. Nakano, S. Ariyoshi, M. Osugiyama,

T. Hayashi, Nichi-Chiku-Kaie (Jap. J. of Zootechnical Sci.

Bulletin) 508 95-99, 1979