Fishery Bulletin

Age, growth, mortality, and distribution of pinfish in Tampa Bay and adjacent Gulf of Mexico waters – Lagodon rhomboides

Age, growth, mortality, and distribution of pinfish in Tampa Bay and adjacent Gulf of Mexico waters – Lagodon rhomboides – Statistical Data Included

Gary A. Nelson

Abstract–Life-history dynamics of pinfish (Lagodon rhomboides) were examined from data derived from random-station surveys conducted in Tampa Bay and adjacent Gulf of Mexico waters during 1993-97. In addition, patterns in spatial distribution and abundance in Gulf of Mexico waters were investigated. Ages determined from whole otoliths ranged from 0 to 7 years, and yon Bertalanffy growth models for males and females were not significantly different. Von Bertalanffy growth model parameters were [L.sub.infinity]=219.9 mm SL, k=0.33/yr, and [t.sub.0]=-1.10 years for all fish combined. High gonadosomatic indices during October-December indicated that some spawning may occur in Tampa Bay. Estimated lengths at 50% maturity were 132 mm SL for males and 131 mm SL for females. Total instantaneous mortality rates derived from the Chapman-Robson estimator ranged from 0.88 to 1.08/yr, and natural mortality was estimated to be 0.78/yr. In Gulf of Mexico waters, pinfish catch rates declined with increasing depth, and most pinfish were caught in <17 m of water. Length distributions showed that pinfish segregate by size with increasing depth.


The pinfish (Lagodon rhomboides) is an ecologically important sparid that inhabits estuarine and offshore waters of the United States from Massachusetts to Texas (Darcy, 1985). Young-of-the-year pinfish are predators on a range of invertebrates in estuaries, often to the degree that entire assemblages of macrobenthic fauna are affected (Young et al., 1976; Young and Young, 1977; Nelson, 1978). They also consume seagrasses during their estuarine phase, which makes them an important link between primary and secondary production (Stoner, 1982; Weinstein et al., 1982; Montgomery and Targett, 1992). Both young-of-the-year and adult pinfish are prey for other fishes (Gunter, 1945; Darnell, 1958; Carr and Adams, 1973; Seaman and Collins, 1983) and are used as bait for many recreationally and commercially important species.

Despite their ecological and economical importance, the population biology and dynamics of pinfish in Florida have not been adequately examined. Most knowledge about growth (Reid, 1954; Caldwell, 1957; Hellier, 1962; Nelson, 1998), distribution and migration (Caldwell, 1957; Hansen, 1970; Nelson, 1998), and mortality (Nelson, 1998) comes from studies of young-of-the year pinfish in estuaries. The only information available on older individuals comes from estuarine studies that describe size and age at spawning (Caldwell, 1957; Hansen, 1970), gross fecundity (Caldwell, 1957), and longevity and size at age (Hansen, 1970). However, that information may contain biases because sampling did not extend into offshore waters where larger, and presumably older, pinfish are thought to occur, particularly during cooler months (Darcy, 1985).

In this study, age, growth, mortality, and maturation of pinfish were evaluated by studying data from multigear fisheries-independent surveys conducted in Tampa Bay, Florida, and in offshore waters off west-central Florida. In addition, patterns in abundance and spatial distribution of pinfish in the Gulf of Mexico were examined.



Pinfish for aging, maturity, and mortality analyses (n=711) were collected opportunistically from fall 1993 to spring 1997 during multiple fisheries surveys conducted in Tampa Bay and offshore Gulf waters by the Florida Marine Research Institute (Fig. 1). Pinfish from Tampa Bay were collected primarily during multigear seasonal (spring and fall) and monthly fisheries-independent surveys designed to estimate relative abundance of small estuarine fishes and evaluate life-histories parameters of large estuarine fishes (Table 1). During the surveys, sites were chosen by randomly selecting 1″ latitude x 1″ longitude microgrids, representing the site to be sampled, within randomly selected 1′ latitude x 1′ longitude grids. At each site, gears were deployed with standardized procedures (see Nelson [1998] and Tremain and Adams [1995] for detailed description of the survey design and deployment techniques). Selected individuals were immediately placed on ice 30% for transport and frozen whole at the laboratory.


Pinfish from the Gulf of Mexico were collected primarily during a bottom-trawl survey conducted in spring in the Gulf of Mexico to document baitfish abundance and distribution. The Gulf trawl survey was conducted during April from 1994 to 1997 at stations randomly selected along line transects randomly placed perpendicular to the west coast of the Florida peninsula adjacent to Tampa Bay. At each station, a 19.8-m, 254-mm stretched-mesh modified ballon trawl with 25.4-mm codend liner and 2.2-[m.sup.2] China V-doors was towed at approximately 3 knots for 30 min during daylight hours in depths ranging between 6 and 31 m. At each station, trawl catches were sorted by species, counted, weighed collectively, and 50 individuals per haul were measured to the nearest I mm fork length (see Pierce and Mahmoudi [2001]) for a detailed description of the survey design). Depth (m) at the start and end of the trawl tow and surface salinity and temperature were recorded at all stations. To match data collected from the Tampa Bay samples, all length data were converted to standard length by using conversion equations derived from this study. Individual fish were immediately frozen whole and returned to the laboratory. Occasionally, supplemental samples were collected by hook-and-line fishing in Tampa Bay and the offshore waters (Table 1).

In the laboratory, standard length (SL [+ or -] 1 mm), fork length (FL [+ or -] 1 mm), total length (TL [+ or -] 1 mm) and total weight (TW [+ or -] 0.01 g; measured after each individual was blotted dry) were recorded for all thawed, undamaged individuals. Gonads were excised from a subsample of individuals (~80%) of each collection, identified macroscopically (and microscopically if needed) as ovaries or testes, blotted dry on a paper towel, and weighed ([+ or -] 0.01 g). Seasonal conversion equations for length measurements were generated by least-squares regression (SAS, 1990a).

Age and growth

Sagittal otoliths for aging studies were excised, cleaned of extraneous tissue, and stored dry in vials. Otolith length was measured under a binocular dissecting microscope at 10x with a calibrated ocular micrometer, and an otolith length (mm) versus fish standard-length relationship was derived by using least squares regression. For age determination, one whole otolith (either left or right) was placed on black velvet to enhance the visibility of opaque zones, submerged in a 60% glycerin solution, and viewed at 32x with reflected light. Otolith edges were classified as either opaque or hyaline to determine time of opaque ring formation. The number of opaque rings was considered to equal the age in years of the pinfish. Age determinations were repeated three times on all whole otoliths. If two of the three age readings were in agreement, the value was accepted. If age varied between all readings, the structure was not included in the analysis. The accuracy with which whole otoliths can be used to age pinfish was confirmed by comparing whole otolith ages from a subsample of the largest pinfish to age readings made on thin sections of the same otoliths. Methods of Hood and Johnson (1999) were used to section otoliths. To verify the consistency of the opaque ring counts, a random subsample (13%) of all whole otoliths was aged once by an experienced second reader and the results were compared to the final age determination. Pinfish larvae are present off the west coast of Florida between November and February (Darcy, 1985); therefore a 1 January birthdate was assumed for all pinfish. Age in years was designated with a decimal extension that represented the date of capture in days from the 1 January birthdate.

Growth was modeled by fitting length-at-age for all years combined to the von Bertalanffy equation:

[L.sub.i,t] = [L.sub.[infinity]] * (1- [exp.sup.(-k*(age-[t.sub.0]))) + [[epsilon].sub.ij],

where [L.sub.i,t] = the standard length of the i th individual at age t;

[L.sub.[infinity]] = the asymptotic maximum length;

k = a growth constant;

[t.sub.0] = the hypothetical age at which length is zero; and

[[epsilon].sub.ij]s = independent, identically distributed, normal random errors.

Parameters L, k, and [t.sub.0] were estimated by using SAS nonlinear regression (Proc NLIN) with the Marquardt method (SAS Institute, 1990b). Lack of fit was assessed by using residuals plots (Bates and Watts, 1988).

Growth-rate differences between sexes were investigated by using an approximate randomization test to compare growth curves (Helser, 1996). Essentially, differences were investigated by comparing an observed test statistic to an empirical probability density function of a test statistic under the null hypothesis of no difference. The observed test statistic for pinfish was developed by fitting the von Bertalanffy growth functions to length-at-age data for sexes combined and to length-at-age for each sex separately. The sums of the residual sum of squares from the two sex-specific models were then used to calculate the observed test statistic

t([x.sub.0]) = [summation over (i,t)[([l.sub.i,t]-[l.sub.t]).sup.2]- [summation over (l,t,p)[([l.sub.i,t,p]-[l.sub.t,p]).sup.2],

where t([x.sub.0]) = the test statistic;

[l.sub.t] = the predicted length-at-age for all sexes combined; and

[l.sub.t,p] = the predicted length-at-age for each sex (p=1,2) (Helser, 1996).

To generate the empirical probability density function (pdf), length-at-age data for both sexes were pooled and then assigned randomly without replacement to two groups with sample sizes equal to the original number of observations per sex. Growth curves were then fitted separately to the length-at-age data of the randomized groups, and the test statistic under the null hypothesis of no difference was calculated as

t(x) = [summation over (i,t) [([l.sub.i,t]-[l.sub.t]).sup.2] – [summation over (i,t,p) [([l.sup.*.sub.i,t,p]-[l.sup.*.sub.t,p).sup.2],

where t(x) = the difference in residual sum of squares between the von Bertalanffy fits to the entire pooled data set and von Bertalanffy fits to the randomized groups (denoted by *).

The randomization procedure was repeated 1000 times to obtain the pdf of t(x). The null hypothesis of no difference was rejected if t([x.sub.0])>t(x) at [alpha]=0.05.

Reproduction, sex ratios, and maturity

Gonads excised from selected individuals were classified macroscopically as either immature or mature by using the maturation criteria of Nikolsky (1963) and Cody and Bortone (1992). Seasonality of reproduction was determined by noting when changes in the gonad condition took place. A gonadosomatic index (GSI) was calculated to show changes in gonad weight in relation to gonad-free total body weight. The index was computed as

GSI = gonad weight/(total body weight – gonad weight) x 100.

Length at 50% maturity was estimated for pinfish captured during the season of gonadal maturation. The probability of pinfish being mature was modeled as a logistic function of the following form:

[P.sub.i] = [exp.sup.([alpha]+[beta]*[x.sub.i])] / 1 + [exp.sup.([alpha]+[beta]*[x.sub.i]) + [[epsilon].sub.i],

where P = the response probability;

x = the standard length (mm) of the i th fish;

[alpha] = the intercept;

[beta] = the slope coefficient of standard length; and

[[epsilon].sub.i] = the error term.

Model regression coefficients were estimated using maximum likelihood (SAS, 1997). Goodness-of-fit was assessed with the chi-square test.

Chi-square analyses were used to test for deviations from a theoretical 50:50 sex ratio.

Length-weight relationships

Because of the seasonality of reproduction, data on body length and weight were separated into two groups representing two time periods to construct length-weight relationships that reflected seasonal changes in gonad weight. Data collected during March-August composed the data group representing the spring-summer period, and data collected during September-February composed the data group representing the fall-winter period. Seasonal regression equations for [log.sub.10]-transformed standard length and body weight (total and gonad-free weight) were generated by the least-squares regression. One-way analysis of covariance (Sokal and Rohlf, 1981), conducted by using SAS PROC MIXED (Littell et al., 1996), was used to test for differences between regression slopes and adjusted means of the length-weight relationships by sex and season.


Total instantaneous mortality (Z) was estimated in Tampa Bay and the Gulf of Mexico from pinfish numbers-at-age data by using the Chapman-Robson equation for survival (S) estimation:


where ln = the natural log;

[x.sub.I] = the number of years the i th fish is older than the age-at full-recruitment;

S = annual survival; and

n = the total number of fully recruited fish (Chapman and Robson, 1960).

The variance of Z was estimated from the variance of S by

V(Z) = S[(1 – S).sup.2] / n * [S.sup.2]

(Jensen, 1985). The Chapman-Robson estimator was used because it is more robust to sample size variation in numbers-at-age (Jensen, 1996; Murphy, 1997).

In addition to Z, natural mortality (M) of pinfish was estimated by using a multiple regression equation relating M to [L.sub.[infinity] (TL in cm) and k (per yr) of the von Bertalanffy equation, and to mean annual water temperature ([degrees]C)(Pauly, 1980). To estimate the growth parameters used in the equation, the von Bertalanffy function was refitted to total length and age data. Mean annual water temperature was estimated from temperature data of the Tampa Bay survey.


To determine if pinfish catch rates in the Gulf of Mexico were associated with depth, a generalized linear model (McCullagh and Nelder, 1989) was used to model the random trawl catches during the April survey from 1994 to 1997. Catch data were transformed by using ln(x+1) to stabilize the variance and reduce the influence of sampling variability between tows. Year, average depth of the trawl tow, and their first-order interaction were included in the model. Only depth was analyzed because surface readings of temperature and salinity were thought to not reflect bottom conditions where the trawl tows were made. Size structure of pinfish caught during the Gulf of Mexico survey was also examined by calculating summary statistics (mean and percentiles) of length data to identify patterns related to depth.



Length-conversion equations are listed in Table 2. All slopes and intercepts were significantly different from zero.

Age and growth

Age determination was based on sagittae from 658 pinfish (66-255 mm SL). Alternating opaque and hyaline zones, which composed an annual growth increment, were evident on whole pinfish otoliths (Fig. 2A). Only 13 otoliths were considered unreadable. Agreement between the number of opaque bands counted on whole otoliths and the number counted on sections of the same otoliths (Fig. 2B) was 96.3% (26/27), indicating that whole otoliths can be used to reliably age pinfish. The high percentage of agreement (89.6%) between the author’s final annulus counts and those made by a second reader, and no apparent bias towards a particular aging error, indicated that ages were consistently interpreted.


Plots of the monthly proportions of otolith with opaque edges for pinfish ages 1 to 3 indicated that an opaque ring is formed only once a year, during late winter to late spring. Deposition of opaque material began as early as January; it peaked during March, April, or May depending on age; and it was completed, or nearly so, by June (Fig. 3).


A single regression equation characterized the relationship between otolith length (OT in mm) and standard length for a random sample of pinfish 71-230 mm SL (standard errors are in parentheses) used in age analysis:

OT = 8.03(1.07) + 0.39(0.008) x SL; [[r.sup.2] = 0.95, n = 132].

The intercept and slope coefficients were significantly different from zero (P<0.001).

Ages of pinfish ranged from 0 to 7 years (66-255 mm SL) in Tampa Bay and from 1 to 6 years (95-175 mm SL) in the Gulf of Mexico (Fig. 4A). The majority (88.1%) of aged pinfish were [+ or -] 2 years. Residual plots from the growth models showed near-random patterns, indicating that the yon Bertalanffy model adequately described the growth of male and female pinfish. Results of the randomization test did not indicate a significant difference between male and female growth models (t([x.sub.0])=2,691;p(t(x)>t([x.sub.0]))=0.27); therefore, a von Bertalanffy model was fitted to all pinfish data combined (Fig. 4B, Table 3). Growth rate of pinfish was rapid for the first 1-3 years of life but gradually decreased thereafter (Fig. 4B).


Reproduction, maturity, and sex ratios

Seasonality of reproduction was indicated by monthly changes in the GSIs of all pinfish over time. In Tampa Bay and the Gulf of Mexico, GSIs for males and females were [+ or -] 0.5% during the spring and summer months (Fig. 5). GSIs began to increase in October (females) and November (males) in Tampa Bay. The highest GSIs for males and females in Tampa Bay were 5% and 8%, respectively, observed in December. High and moderate GSIs for females and males during January in the Gulf of Mexico indicated continued spawning, but low values in April suggested that spawning ended prior to that month (Fig. 5).


Maturity of male and female pinfish was related significantly to length (male: Wald [[chi].sup.2]=18.8, P [less than or equal to] 0.001; female: Wald [[chi].sup.2]=32.1, P [less than or equal to] 0.001) by logistic equations, and there was no evidence of lack of model fit (male: [[chi].sup.2]=81.1, df=94, P=0.82, max-rescaled [r.sup.2]=0.38; female: [[chi].sup.2]=109.2, df=121, P=0.77, max-rescaled [r.sup.2]=0.60). Parameter estimates (standard error) were [alpha] = -7.78 (1.745) and [beta] = 0.06 (0.014) for males, and [alpha] = -9.83 (1.721) and [beta] = 0.08 (0.013) for females. The estimates of length at 50% maturity [+ or -] 95% C.I. were similar for both sexes: 132 [+ or -] 8 mm SL for males and 131 [+ or -] 8 mm SL for females. The smallest mature male was 112 mm SL and the smallest mature female was 92 mm SL. The largest immature male pinfish was 245 mm SL and female pinfish was 173 mm SL.

Chi-square tests indicated that sex ratios did not deviate significantly (P>0.05) from unity in any season.

Length-weight relationships

No significant differences (P [less than or equal to] 0.10) in slopes or intercepts of standard-length on body-weight relationships were observed between sexes in any period; therefore all data were pooled for the subsequent analyses. Seasonal length-weight regressions for both sexes combined are listed in Table 2 for total and gonad-free body weight. Regression slopes were significantly different between periods only for the standard-length on total-body-weight relationship (P [less than or equal to] 0.01). The regression slope was highest in fall-winter, which indicates that pinfish gain more weight per unit increase in length during this period than in spring-summer. Adjusted means for the standard-length on gonad-free body-weight relationship were not significantly different between periods (P>0.05).


Based on frequency plots by age, age-at-full-recruitment was age 1 for pinfish in Tampa Bay and age 2 for those in the Gulf of Mexico. Estimates of Z were 1.08/yr for Tampa Bay pinfish and 0.88/yr for the Gulf of Mexico pinfish (Table 4). Estimates of Z for all areas combined, assuming full recruitment at age 2, were intermediate to the Z estimates made for each area separately (Table 4).

The estimate of M was 0.78/yr from Pauly’s (1980) multiple regression equation by using [L.sub.[infinity]] = 30.1 cm, k=0.31/yr, and mean annual temperature of 24[degrees]C.


In the Gulf of Mexico, pinfish were captured at 90% (55/61) of sites where trawls were pulled in depths of 6 to 30 m during the baitfish survey (Fig. 6). Catch rates of pinfish in the Gulf of Mexico varied significantly between years and were associated with depth, but the significant interaction term indicated that the relationship between depth and catches varied between years (Table 5). Plots of cumulative proportions of total catches by year showed that most trawl catches (95%) occurred in waters <15 m during the 1994, 1995, and 1997 surveys, but in 1996, 95% occurred in waters <17 m (Fig. 7A).


Length summary plots for pinfish caught during the baitfish survey showed that pinfish became segregated by size as depth increased. Median length increased from 109 mm SL in the 6-10-m depth range to 152 mm SL in the 26-30 m depth range (Fig. 7B). The smallest (80-mm-SL) and the largest (203-mm-SL) pinfishes were captured in the 6-10 m and 11-15 m depth ranges, respectively.


Age and growth

This study is the first to report otolith-derived age estimates for pinfish. Hansen (1970) reported scale-derived age estimates for pinfish from a Florida Panhandle estuary. In the current study, annuli were identified and counted on whole otoliths and were then identified and counted on thin sections. The high initial agreement (89.6%) between the age determinations of the author and a second reader suggests a high degree of precision can be attained without sectioning the otolith. Given the high degree of error generally associated with estimating ages of fish from their scales (Jearld, 1983; Beamish and McFarlane, 1987), I believe that age estimations made from pinfish otoliths are far more likely to be accurate.

Deposition of opaque material in the sagittal otoliths of pinfish occurs over a protracted late-winter to early-spring period and indirectly validates the formation of annuli in pinfish. Similarly, Hansen (1970) found that annuli on scales are generally formed once a year, in April.

The maximum age of pinfish determined in this study was 7 years, which exceeded the maximum age of 2 years reported by Hansen (1970). The difference in maximum age is probably due to Hansen’s inadequate sampling of the entire size range of pinfish in Pensacola Bay–he collected pinfish at only two stations using a single, selective trawl. In addition, Hansen’s use of scales as the primary aging structure may have contributed to the underestimate of the maximum age of pinfish (Beamish and McFarlane, 1987). In contrast, pinfish collected in this study were sampled from numerous locations in Tampa Bay and adjacent Gulf waters with multiple types of gears that had various mesh sizes, and otoliths, which are more reliable aging structures than scales (Beamish and McFarlane, 1987), were used for age determination. Coincidentally, Caldwell (1957) projected from the growth rates of age-1 pinfish that a 328-mm-SL pinfish may have been as old as 7 years; my results provide direct evidence that supports his estimate.

Reproduction, sex ratios, and maturity

The monthly changes in GSIs show that pinfish are late-autumn to early-spring spawners in Tampa Bay and adjacent Gulf of Mexico waters; this conclusion was also reported by Darcy (1985) and Cody and Bortone (1992). Pinfish spawning is suspected to occur in offshore oceanic waters (Hansen, 1970; Darcy, 1985); however, the high GSIs of pinfish collected in Tampa Bay and the occurrences of several of these pinfish with late-developing gonads in waters about 3-6 km into the bay during October-December suggest that some spawning activity may occur in this estuary. This is not surprising because most studies that have examined gonadal activity in pinfish have used samples only from offshore waters (Franks et al., 1972; Stott et al., 1980, 1981), did not use gear with various mesh sizes to adequately sample the entire size range of pinfish found in estuaries (Caldwell, 1957; Hansen, 1970), or did not compare data on an estuary-offshore basis (Cody and Bortone, 1992).

Length-weight relationships

The length-weight relationships were affected by gonadal maturation. During the September-February period, gonad weight of both sexes increased, which resulted in a standard-length to total-body-weight relationship that was higher than it was in March-August period. Differences in predicted total weight at length were 2-8% between the September-February and March-August periods and illustrate the effect of maturation on these relationships. The slopes of the length-weight relationships from both periods (3.03-3.11) were higher than the slopes of length on weight relationships (2.91 and 2.90, respectively) developed by Caldwell (1957) and Cameron (1969).


This study is the first to report total instantaneous mortality (Z) rates (0.88-1.08) for pinfish older than young-of-the-year. It is difficult to conclude whether the mortality rate in Tampa Bay is really higher than that in the Gulf. The small mesh characteristics of the sampling gear, the restricted spatial coverage of sampling from Tampa Bay to the shallows of the estuary where young pinfish dominate (most gears were employed in waters <3 m), or the migration of pinfish from estuaries to offshore waters to spawn may have contributed to the older (>age 1) fish being underrepresented in the sampling of bay waters (Hansen, 1970; Darcy, 1985; Nelson, 1998). By assuming that pinfish are fully recruited at age 2 (Table 4), I estimated that Z from data for both areas combined is probably more realistic because the numerical proportions of pinfish ages 2 and older in Tampa Bay were nearly identical to the numerical proportions of pinfish age 2 and older from the Gulf of Mexico. The estimate of Z from data for both areas combined (0.90/yr) was close to the natural mortality estimate of 0.78/yr, suggesting that the portion of annual mortality attributed to fisher activity, calculated by (Z-M)/Z, is low [13%].


Darovec (1995), Franks et al. (1972), and Darcy and Gutherz (1984) reported that pinfish from the Gulf of Mexico occurred in trawls to depths between 73 m and 93 m. However, most pinfish captured in Gulf waters off west-central Florida were captured from depths <19 m (Darovec, 1995). The results from the baitfish survey were very similar in that most pinfish (95%) were caught in waters <17 m, but the abundance-depth relationship varied between years, and larger pinfish were generally associated with greater depths. The propensity of pinfish to limit their depth distribution and alter their size distribution with depth is probably due to the distribution of their epibenthic prey (Stoner, 1980; Nelson and Bortone, 1996), the distribution of their predators, and (because pinfish are visual feeders) reduced light intensity with depth (Kjelson and Johnson, 1976; Luczkovich, 1988).

In summary, ages determined from whole otoliths ranged from 0 to 7 years, and von Bertalanffy growth model parameters for all aged fish were [L.sub.[infinity]] =219.9 mm SL, k =0.33/yr, and [t.sub.0] =-1.10 years. High gonadosomatic indices during October-December indicated that some spawning may occur in Tampa Bay. Estimated lengths at 50% maturity were 132 mm SL for males and 131 mm SL for females. Total instantaneous mortality rates from the Chapman-Robson estimator ranged from 0.88 to 1.08/yr, and natural mortality based on Pauly’s (1980) equation was 0.78/yr. Catch rates of pinfish were related to depth in the Gulf of Mexico.

Table 1

Length summary statistics (by area, year, and gear) for pinfish

collected during biological sampling. Exp. gill net = experimental

gill net.


SL (mm)


Year Gear mesh (mm) Minimum

Tampa Bay

1993 trammel net 76, 305 179

1995 exp. gill net 50-152 170

183-m seine 38 73

trammel net 76, 305 173

21-m seine 3.2 73

61-m seine 25.4 72

1996 183-m seine 38 66

purse seine 50 100

trammel net 76, 305 203

21-m seine 3.2 34

hook and line — 198

1997 183-m seine 38 83

purse seine 50 91

21-m seine 3.2 25

Gulf of Mexico

1996 hook and line — 116

1997 bottom trawl 254 95

Pinfish SL (mm)

Year Gear Maximum Mean n

Tampa Bay

1993 trammel net 255 211.8 31

1995 exp. gill net 185 180.0 3

183-m seine 202 121.1 50

trammel net 216 191.4 8

21-m seine 150 112.1 24

61-m seine 165 132.6 19

1996 183-m seine 207 126.9 313

purse seine 181 125.9 34

trammel net 203 203.0 1

21-m seine 174 89.0 28

hook and line 205 202.0 3

1997 183-m seine 155 111.3 62

purse seine 156 108.9 16

21-m seine 104 71.7 18

Gulf of Mexico

1996 hook and line 149 135.2 17

1997 bottom trawl 175 128.8 84

Table 2

Linear regression statistics showing the length conversion and

length-weight relationships for pinfish. For the length conversions,

the model is y = [alpha] + [beta] x x. For the weight-length

relationships, the model is [log.sub.10](y) = [alpha] + [beta] x

[log.sub.10]x. [alpha] is the regression intercept, [beta] is the

slope coefficient, [r.sup.2] is the coefficient of determination, n is

the sample size, MSE is the mean square error, FL is fork length (mm),

SL is standard length (mm), TL is total length (mm), GFW is gonad-free

body weight, and TW is total body weight (g). SP-SU is spring-summer

and FA-WI is fall-winter. All slopes and intercepts were significantly

different (P [less than or equal to] 0.05) from zero. Slopes between

TW-SL relationships were significantly different

(P [less than or equal to] 0.01).

y x Season [alpha] SE([alpha]) [beta]

FL SL All 2.65 0.368 1.14

TL SL All -2.20 0.542 1.33

TL FL All -3.73 0.412 1.15

GFW SL SP-SU -4.56 0.061 3.04

TW SL SP-SU -4.53 0.045 3.03

GFW SL FA-WI -4.57 0.064 3.07

TW SL FA-WI -4.68 0.043 3.11

y x SE([beta]) [r.sup.2] n MSE

FL SL 0.003 0.996 603 4.736

TL SL 0.004 0.994 625 13.745

TL FL 0.003 0.997 591 5.695

GFW SL 0.029 0.977 257 0.0020

TW SL 0.021 0.983 343 0.0020

GFW SL 0.030 0.977 244 0.0024

TW SL 0.021 0.987 302 0.0023

Table 3

Estimates of the von Bertalanffy growth parameters for

pinfish by sex and for all sexed and unsexed fish combined.

MSE is the mean square error, [r.sup.2] is the coefficient of

determination, and n is the sample size. Asymptotic standard

errors are shown in parentheses.

Sex [L.sub.[infinity]] k [t.sub.0]

Male 228.5 0.31 -1.21

(19.733) (0.079) (0.331)

Female 212.0 0.33 -1.16

(16.504) (0.082) (0.309)

All fish 219.9 0.33 -1.10

(12.204) (0.055) (0.203)

Sex MSE [r.sup.2] n

Male 517.926 0.57 285

Female 551.020 0.51 330

All fish 537.490 0.55 645

Table 4

Estimates of annual survival (S) and total instantaneous mortality (Z)

of pinfish determined by using the Chapman-Robson (1960) estimator for

Tampa Bay, the Gulf of Mexico, and both areas combined. [n.sub.r] is

the sample size at each age of full recruitment and [n.sub.a] is the

number of age classes included.

Age (yr) at full

recruitment [n.sub.r] [n.sub.a]

Tampa Bay (n=549) 1 379 7

Gulf of Mexico (n=96) 2 70 5

Combined (n=645) 2 189 6

Estimate Variance


Tampa Bay (n=549) 0.34 1.08 0.0004 0.0033

Gulf of Mexico (n=96) 0.41 0.88 0.0020 0.0120

Combined (n=645) 0.40 0.90 0.0008 0.0043

Table 5

Results of the generalized linear model analysis of ln (x+1)

pinfish catches (in number per [nmi.sup.2]) from the baitfish

cruises in the Gulf of Mexico, 1994-97.

Source df MS F [r.sup.2]

Model 7 79.9 16.1 *** 0.680

Year 3 25.5 5.1 ***

Depth 1 389.3 78.4 ***

Year x depth 3 31.3 6.3 ***

Error 53 5.0

Corrected total 60 13.7

*** =P [less than or equal to] <0.001.


Support for this study was provided in part by the State of Florida Recreational Fishing License and in part by the Department of the Interior, U. S. Fish and Wildlife Service, Federal Aid for Sportfish Restoration, project number F-43 to the Florida Fish and Wildlife Conservation Commission. I thank the staff of the Fisheries-Independent Monitoring Program at the Florida Marine Research Institute for their dedication to sampling. B. Mahmoudi and D. Pierce provided the baitfish cruise data. M. Murphy was the second age reader. E. Robillard and D. Merryman sectioned the otoliths. F. Astaire provided encouragement throughout the study. Comments by L. Barbieri, L. Bullock, R. Cody, J. Lieby, J. Quinn, R. Taylor and two anonymous reviewers improved the quality of the manuscript.

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Manuscript accepted 15 February 2002. Fish. Bull. 100:582-592 (2002).

Gary A. Nelson

Florida Fish and Wildlife Conservation Commission

Florida Marine Research Institute

100 Eighth Avenue SE

St. Petersburg, Florida 33701

Present address: Massachusetts Division of Marine Fisheries

Annisquam River Marine Fisheries Station

30 Emerson Avenue

Gloucester, Massachusetts 01930

E-mail address: Gary.

COPYRIGHT 2002 National Marine Fisheries Service

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