 Research article
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Best fitting tumor growth models of the von BertalanffyPütterType
BMC Cancervolume 19, Article number: 683 (2019)
Abstract
Background
Longitudinal studies of tumor volume have used certain named mathematical growth models. The BertalanffyPütter differential equation unifies them: It uses five parameters, amongst them two exponents related to tumor metabolism and morphology. Each exponentpair defines a unique threeparameter model of the BertalanffyPütter type, and the abovementioned named models correspond to specific exponentpairs. Amongst these models we seek the best fitting one.
Method
The best fitting model curve within the BertalanffyPütter class minimizes the sum of squared errors (SSE). We investigate also nearoptimal model curves; their SSE is at most a certain percentage (e.g. 1%) larger than the minimal SSE. Models with nearoptimal curves are visualized by the region of their nearoptimal exponent pairs. While there is barely a visible difference concerning the goodness of fit between the best fitting and the nearoptimal model curves, there are differences in the prognosis, whence the nearoptimal models are used to assess the uncertainty of extrapolation.
Results
For data about the growth of an untreated tumor we found the best fitting growth model which reduced SSE by about 30% compared to the hitherto best fit. In order to analyze the uncertainty of prognosis, we repeated the search for the optimal and nearoptimal exponentpairs for the initial segments of the data (meaning the subset of the data for the first n days) and compared the prognosis based on these models with the actual data (i.e. the data for the remaining days). The optimal exponentpairs and the regions of nearoptimal exponentpairs depended on how many datapoints were used. Further, the regions of nearoptimal exponentpairs were larger for the first initial segments, where fewer data were used.
Conclusion
While for each near optimal exponentpair its best fitting model curve remained close to the fitted data points, the prognosis using these model curves differed widely for the remaining data, whence e.g. the best fitting model for the first 65 days of growth was not capable to inform about tumor size for the remaining 49 days. For the present data, prognosis appeared to be feasible for a time span of ten days, at most.
Background
BertalanffyPütter differential equation
Historically, the systematic application of mathematical models for tumor growth has begun in the 1960s [1,2,3]. In the meantime, so many different approaches towards modeling were developed that concerns about a “model muddle” have evolved [4,5,6]. The focus of this paper is on longitudinal studies of tumor volume, which use tumor growth curves that are defined from certain first order ordinary differential equations [7]. Such studies aim at biophysical explanations for tumor growth and at tools for prognosis and therapy [8,9,10]. In this context, the BertalanffyPütter [11,12,13] differential eq. (1) has been recommended as “a macroscopic model variant that can be conceived as an optimal condensed modeling approach that to a high degree preserves complexity with respect to … more complex modeling variants” [14]:
This equation describes tumor volume v(t) in mm^{3} over time t in days, using five model parameters that are to be determined from fitting the model to sizeatage data: Four parameters are displayed in the equations, namely the nonnegative exponentpair a < b and the constants p and q. A fifth parameter is the initial tumor volume at the start of monitoring, i.e. v (0) = v_{0} > 0.
In this paper, we perceive eq. (1) as a definition of a twoparameter family of growth models, whereby each exponentpair (a, b) defines a unique model with three free parameters (p, q, and v_{0}). Thus, for these models the “model muddle” can be reduced by considering them within the context of the larger unifying class (1) of models. Figure 1 displays (in blue) several “named models” that can be defined from certain exponentpairs and displays (in yellow) additional exponentpairs that in view of their closeness to the named ones we deemed as biologically meaningful; we considered them for an initial search. For example, the exponentpair (a, b) = (0, 1) defines exponential growth (i.e. v(t) = v_{0}·e^{q·t}, assuming p = 0, q < 0), and bounded exponential growth (i.e. v(t) = (p/q)·(1d·e^{q·t}), assuming p, q, v_{0} > 0 and defining d from these parameters). The logistic growth model of Verhulst [15] is defined from eq. (1) using the exponentpair (a, b) = (1, 2). The Gompertz [16] model is the limit case a = b = 1; it uses a different differential equation [17]. These models are amongst the most common models in this field (Google Scholar: 237,000 hits for “tumor growth model, exponential growth”, 122,000 hits for “tumor growth model, logistic” and several thousand hits for other named growth models).
Richards’ [18] model (Fig. 1: grey line a = 1, b > 1) and the generalized Bertalanffy model (Fig. 1: grey line b = 1, 0 ≤ a < 1) are represented as classes of models. In the theory of economic growth, the latter model (class) is known as SolowSwan model [19,20,21,22].
A drawback of this type of phenomenological models is the difficulty in relating the comparatively easy to observe macroscopic data (sizeatage) to actual biological processes. According to von Bertalanffy [11, 14], the parameters of eq. (1) relate to resource utilization, metabolism and morphological structures of tumors: [11] has chosen the exponent a = 2/3, as the inflow of energy would be proportional to the surface area (i.e. proportional to volume^2/3), and the exponent b = 1, as the energy needs for sustenance would be proportional to volume (cell count). This model appears to be plausible for the avascular stage of a solid tumor (nutrients enter only through the periphery). However, other authors proposed different biophysical explanations of growth and different exponentpairs [23, 24]. Thus, the tumor surface may be fractal, whence the first exponent (a) may be above the value 2/3 of [11]. Further, as noted by [25], a static biomechanical explanation of growth may not capture growth for changing biological drivers due to e.g. the formation of new blood and lymphatic vessels (angiogenesis, lymphangiogenesis) or due to growth beyond the bounds of the original organ (extracapsular extension). [26, 27] analyzed the reasoning of [11] in the context of the biology of fish and they recommended the use of more general model classes, namely the generalized Bertalanffy model and later all models for eq. (1). Other authors recommended the analysis of the relative growth rates v´/v over time, as these would inform about metabolism [28].
A different modeling approach describes tumor growth at the more detailed tissue scale in terms of partial differential equations related to invasionproliferation and diffusionreaction; e.g. FisherKolmogorov equation [29, 30]. For such an approach the explanations of growth rest on firm theoretical ground, but for the study of concrete tumors complex data about their spatial evolution over time would be needed; simple sizeatage data would not suffice.
Problem of the paper
We reconsider the findings of [31]. They compared seven models. Of them, the models of von Bertalanffy, Gompertz, and Verhulst, would be “particularly popular choices for modeling tumor growth … because they include a biologically realistic slowing of the growth rate as the tumor increases. Yet it is precisely this feature that results in the poor predictive value of the models.” They supported their claim through data, where the best fitting model underestimated future tumor growth.
As these findings depended on a few models only, and as there is no generally valid tumor growth model, which ensures a clear understanding and prognosis of tumor growth, the present paper revisits this issue and considers models from a more comprehensive class. The differential eq. (1) defines such a class that encompasses the most popular models (see above). We therefore aim at comparing the models from the model class (1) in terms of their goodness of fit (see methods) to the data of [31] and we assess their utility for prognosis.
This approach has the following advantages: First, using a larger class of models with different growth patterns for comparison will provide a high flexibility in datafitting and results in a better fit of the overall optimal model; for such a model we expect a better prognosis. Second, using a large class of models allows for a better comparability of the results with the literature. For even if a certain model may not be an element of the large class, some other element of the class may approximate it. And third, this approach allows estimating the uncertainty of prognosis. We claim that there may be limits to prognosis that are inherent to the research problem (c.f. prognosis of weather), and that nearoptimal models might highlight these limits. For nearoptimal models [32,33,34] the fit to the data does not differ significantly from the best fit model (see methods), but their forecasts may differ. This approach improves upon the traditional sensitivity analyses (variation of model parameters) insofar, as for the present models and data even slight changes in the parameters (some parameters are of size 10^{− 30}) may result in very poorly fitting model curves.
This working plan has not yet been implemented in literature, because the optimization of the five parameters a, b, p, q, and v_{0} of (1) may fail with standard optimization software. We will therefore also explain the optimization tools.
Methods
Data
We aim at explaining the findings of [31] and we therefore use the data of that paper; they originate from [35]. Human breast cancer cells of type GI101A were injected subcutaneously into nude mice and the subsequent tumor growth was observed for 114 days for a treatment group and a control group (8 animals). At 14 points of time tumor volume was measured (Table 1); Fig. 2 plots the data and an interpolation function that was obtained by the method of cubic splines [36].
We demonstrate our method to find the best fitting and the nearoptimal models for this dataset, only, as the paper aims at a “proof of principle”. While the conclusions about the limitations of prognosis may not apply to other data, the method to obtain such conclusions for concrete data generalizes. As a visual inspection of the data (Fig. 2) would suggest that the first and the second half of the growth process may have been driven by different biological processes (steeper slope for the second half), there also arises the question, if a single model of the type of eq. (1) suffices to approximate the data accurately. (If two models were needed to describe two phases of growth, this would require 11 parameters, five for each model and one for the moment of model change. Reasonable modeling would require significantly more datapoints.)
Models
The yellow region in Fig. 1 displays the models that we considered initially; i.e. each of the displayed exponentpairs defined a unique model of type (1) with three free parameters. For numerical purposes, we worked with an accuracy of 0.01 for the exponentpairs, whence we considered only exponentpairs on a grid (a = m·0.01, b = a + n·0.01, with integers m ≥ 0, n ≥ 1). If the exponentpair of the best fitting model was attained on the upper boundary line or on the right boundary line of this grid (yellow region of Fig. 1), then further gridpoints were added for the search to verify the optimality of this exponentpair or replace it by a better one.
The diagonal a = b was not considered, as for exponents a = b the differential eq. (1) needs to be replaced by another differential equation from [17] of the Gompertztype (e.g. the Gompertzmodel for a = b = 1). Thus, if the exponentpair with the best fitting model curve was a grid point next to the diagonal, then there remained the possibility that a Gompertztype model could fit better. However, we expected that the improvement would be small. For, as noted by [17], the Gompertztype models are limits of models of type (1) with exponents a < b.
Fit to the data
[31] assessed the fit of models to data by means of the sum of squared errors SSE, which is defined as follows; v(t) is a solution of eq. (1), using certain exponents a < b and parameters p, q, v_{0}, and v_{i} are the data from above:
Thus, each exponentpair (a, b) defines a unique model from class (1) with three free parameters (p, q, v_{0}). For each of these models (exponentpairs) we wished to identify the best fitting model parameters p, q, v_{0}. Thereby, we used the method of least squares; i.e. for each exponentpair (a, b) on the grid we sought parameters (p, q, v_{0}) that minimized SSE. This defined the following function on the grid to identify, for each exponentpair a < b, the minimal SSE that can be achieved:
In terms of this definition, an exponentpair (a, b) from the grid of Fig. 1 (yellow region) was defined as optimal, if the function SSE_{opt} attained the minimum over the grid at this exponentpair. The exponentpair was defined as nearoptimal, if SSE_{opt}(a, b) was at most a certain percentage (we considered the thresholds 1, 5, and 10%) larger than this minimal SSE.
Using SSE to assess the goodness of fit emphasizes the accuracy of the interpolation by means of the model curve. It is also common in forecasting, whereby the Verhulst and Gompertz models are amongst the most popular growth models in that field [37, 38]. Thus, SSE appears to be suitable for the present paper, as the goal is the study of the limitations of the prognosis of the growth of individual tumors.
As using SSE is based on the implicit assumption that the fit residuals (differences between the observed data and the fitted model curve) are normally distributed, we tested this assumption using the AndersonDarling and Cramérvon Mises distribution fit tests [39]. We investigated also an alternative statistical assumption, a lognormal distribution, where the standard deviation of volume is approximately proportional to volume. However, as the prognosis in this case tended to underestimate growth, the results are not discussed here.
Alternative criteria for model selection, e.g. the wellknown Akaike information criterion AIC [40,41,42], focus on parsimony (suitable e.g. for the comparison of theories of growth). As noted by [31], for their data the most parsimonious of their models, exponential growth, falsely predicted unbounded growth. Therefore, for this paper we do not consider this approach.
Optimization
The computation of SSE_{opt} (i.e. optimization) was done using Mathematica® 12.0 software of Wolfram Research. The authors provide a Mathematica file as supporting material. The output was exported to a spreadsheet, Microsoft Excel®. It is provided as a supporting material in the format (a, b, v_{0}, p, q, SSE_{opt}(a, b)) of the table.
For optimization, the gridpoint exponentpairs (a, b) were visited by means of an outer loop running through a = m·0.01 and an inner loop that for each a ran through the values b = a + n·0.01. Given (a, b), the optimization of p, q, and v_{0} was done using a custommade variant of the method of simulated annealing [43], as this made the optimization process fully automated. A typical step of simulated annealing started with given candidates p, q, v_{0} > 0 for optimal parameters. The candidate parameters were altered by multiplying them with positive random numbers close to 1. (This preserved positivity in order to obtain bounded growth curves and insofar it differed slightly from the conventional approach of adding small random numbers.) These new parameters were accepted as new candidates, if for them SSE became smaller, but in order to escape from suboptimal solutions, with a certain probability new parameter values were also accepted, if for them SSE became larger. (Otherwise, the old candidates were retained.) This step was then repeated with the accepted parameter. At the begin of each inner loop, i.e. at a grid point near the diagonal of the form (a, a + 0.01), the optimization of p, q, v_{0} used 50,000 of these simulated annealing steps, starting with the estimate p = q = 1 and the initial condition v(t_{1}) = v_{1} (first data point). For the subsequent grid points in the bdirection (inner loop), the previous optimization results were used as starting values and improved in 10,000 annealing steps. Thereby, after each 1000 steps the simulated annealing restarted with the hitherto best parameters. Further, the probability of accepting parameters with a higher SSE was lowered slightly. (This was made dependent on the hitherto obtained optimization results and is known as adaptive cooling: [43].) To assess the output, a plot of the nearoptimal exponentpairs with threshold 1% for nearoptimality (i.e. SSE_{opt} exceeded the minimum SSE by at most 1%) was visually inspected. Where the plot had a frayed appearance, the optimization exercise was repeated with more simulated annealing steps. CPUtime for the computations took about one week.
The optimal parameters from simulated annealing were finally used as starting values for a nonlinear regression for the model with the optimal exponentpair, using standard methods to determine v_{0}, p, q (Mathematica command NonlinearModelFit) and further improve SSE_{opt}.
Results
Growth over 114 days
The best fitting model satisfying eq. (1) was sought for. Figure 3 plots the extended search grid, the optimal and the nearoptimal exponentpairs for different thresholds. Simulated annealing achieved the best fit SSE_{opt} (1.62, 2.44) = 1.274·10^{5} with the parameters v_{0}, p, and q from the caption of Fig. 3. Another round of simulated annealing (50,000 steps to optimize also the exponentpair) did not improve the solution. However, using the parameters v_{0}, p, and q as starting values for a standard nonlinear regression for the model defined from the exponentpair a = 1.62, b = 2.44 resulted in a slight improvement below the displayed accuracy. Figure 4 plots the best fitting model curve. For comparison, amongst the seven models of [31] the best fit was achieved for the logistic model (Verhulst) with SSE_{opt} = 1.61·10^{5}. ([31] obtained the slightly worse value SSE_{opt} = 1.67·10^{5}: Fig. 3 of the cited paper.) Thus, SSE_{opt} of the Verhulst model exceeded the least SSE by 26%.
The best fitting model curve supported the hypothesis of bounded growth, as its asymptotic volume of 4,034 mm^{3} (computed as the limit of the model curve v(t) for infinite t) remained close to the maximally observed volume (16% increase from 3,503 mm^{3}, whereas 50% increase might be excessive [32]) and as the inflection point could be discerned from the data. (It was attained during the observed time span at the volume of 2,450 mm^{3}, which is 70% of the maximally observed volume.) Further, as shown by Fig. 4, the best fitting model curve was close to the data whence there did not arise concerns about outliers in the data or about the convergence of optimization; the standard deviation of the fit residuals was 99 mm^{3}. Distribution fit tests did not refute the implicit assumption for using the method of least squares, normally distributed fit residuals (pvalue 0.42 for a sign test for median 0 and pvalues 0.66–0.67 for the AndersonDarling and Cramérvon Mises tests for normality).
Predictive power
To explore the potential for prognosis, [31] fitted several models to the first seven growth data covering a time span of 65 days. This paper therefore repeated the above computations for the data of the first 65, 76, 87, 98, and 107 days and compared them with the full data.
Table 2 reports the optimal exponentpairs and parameters of the best fitting model curves for each of these data and Fig. 5 plots the optimal exponentpairs (labeled by the considered time spans). For the data over a time span of 65 days, [31] identified the von Bertalanffy model as best fitting model and reported SSE = 33,700 (caption to Fig. 1 of that paper). Simulated annealing improved this fit for the von Bertalanffy model to SSE_{opt} (0.67, 1) = 32,177 and identified a still smaller SSE_{opt} (0.68, 0.69) = 32,087 (rounding to integers).
Figure 6 is the counterpart to Fig. 3 but restricted to nearoptimal exponentpairs within the initial search grid of Fig. 1 and using the 5% threshold for defining nearoptimality. (This threshold reduced overlaps.) Except for the data over 65 and 76 days, all optimizations needed extensions of the initial search grid of Fig. 1. Compared to Fig. 3 (gray region) the region of nearoptimal exponents for the data over a time span of 65 days was huge. This high variability indicates that the data did not suffice to identify a suitable growth model. One reason was the small number of only seven points of time for fitting a solution of eq. (1) with five free parameters. This was demonstrated by the region of nearoptimal exponentpairs for the data over a time span of 76 days, which was smaller.
The optimization for the data for 98 and 107 days was particularly time consuming, as 63,377 and 64,150 grid points were searched. For the latter data, Fig. 7 plots the search grid (its zigzag shape was due to the successive addition of grid points) and the optimal (black) and nearoptimal (red, threshold 5%) exponentpairs. For these models, the large exponents, b, necessitated the use of extremely small parameters, q. The frayed character of the red region reflects the numerical problems of using such exponents and parameters; due to such problems conventional allpurpose optimization software was doomed to fail. For the former data, the optimal exponentpair was still on the upper boundary of the search grid, whence the optimality of the exponentpair was not secured.
Figure 8 plots the optimal model curves defined in Table 2. Each model curve had a good fit to the data that it intended to approximate. For most curves the fit to the next data point was acceptable, but the prognosis for more than 10 days was poor.
Discussion
Our results confirm the finding of [31], that the selection of the model with the best fit to an initial segment of the data may “not guarantee the selection of the best model for predicting future behavior”, which we represented by the full dataset. However, our conclusion differs: The failure of prognosis may not necessarily be due to the choice of a false model. Rather it may be the data that limit the time horizon for forecasting.
Figure 8 explains the reasons for the failure of the prognosis for the present data. The red curve was fitted to the first seven data (65 days) and its prognosis for day 76 was acceptable, as it extrapolated the apparent trend, whereas its prognosis for the remaining days was too low. The violet curve (76 days) extrapolated this trend, too, and so its prognosis failed. The blue curve was fitted to the first ten data (87 days) and it correctly identified another trend with a steeper ascent till day 93. However, its extrapolation for the following days was too high. The orange and the gray curves used the first 12 and 13 data points (98 and 107 days) and they identified the slowing down of growth, but they overestimated it and could not forecast the volume for the last data point (day 114). Thus, the present data seemed to display two apparent changes of trend, an acceleration of growth after day 76 and a slowing down after day 93, resulting in the typical Sshape of bounded growth.
For a practitioner, who uses the past data to extrapolate into the future, the failure of forecasting may indicate problems for the patient, e.g. a different phase of growth, where the apparent trend of the growth curve changes due to a biological cause (e.g. angiogenesis). It may indicate problems with the data, such as the presence of outliers. Or it may merely indicate that the true nature of the growth curve could not be identified, because its Sshape could not (yet) be discerned from the data.
For the present data the latter reason may apply, as Fig. 8 displays a growth curve with a good fit to the data (green curve) and Fig. 4 shows that with 95% confidence all observations were within its single prediction band (no outliers). Figures 9 confirms this. It uses the data for all 114 days of observation and plots the relative growth rates v´/v over time for the best fitting models of the top1% of the nearoptimal exponents. Its reverted Ushape suggests that the tumor size may have approached the carrying capacity, whence further growth would be inhibited by lack of resources, unless other drivers of growth (e.g. angiogenesis) were activated. This information might not have been readily available, if v´/v were estimated from a numeric differentiation of the data (blue line).
The analysis of relative growth rates in Fig. 10 confirms the conclusion that the different forecasts may have been due to apparently different trends, that nevertheless could be reconciled into one wellfitting model function. Judging only from the initial data till day 76 the relative growth rate appeared to slow down. With the data for 87 and more days, this picture changed; the best fitting model curves had increasing relative growth rates also for the initial days. However, the data for the first 87 days could not recognize the subsequent slowing of growth. Thereby, owing to the lack of more longterm observations, the models based on the data for 98 and 107 days overestimated this slowing.
Further, the size of the region of nearoptimal exponentpairs is related to the information inherent to the growth data: The larger the region is, the fewer information can be retrieved, as for a larger region the data would be compatible with more (too many) possible shapes of the growth curve. As was shown in Fig. 6, the data for 65 days resulted in a huge region, whence no reliable prognosis could be expected. For the full set of data for 114 days, the region of nearoptimal exponents was smaller (Fig. 3).
Conclusions
For the data of [31] the prognosis of tumor growth was feasible only for a short time span into the future: Past growth data could not identify, if and when there would be a change in the apparent trend or even a change in the biological mechanism of growth. Insofar, the data appeared to be peculiar, but we did not check, if this peculiarity would be typical for growth data of cancer. For instance, concerning biological interpretations of the best fitting model curve, the exponentpairs of the named models were remote from the optimal and nearoptimal exponentpairs for the data over 114 days (Fig. 3). Further, the optimal exponentpairs obtained from initial segments of the data did not show a clear pattern (e.g. convergence) that would relate them to the optimal exponentpair of the data over 114 days (Fig. 5). Thus, the biophysical arguments that supported the named models may not apply in the present context.
However, even for peculiar data, prognosis is not futile, as for practitioners any discrepancy between observed and forecasted growth may be an important warning signal that the tumor biology may change. The present paper provided methods for a more accurate prognosis.
In addition to prognosis, practitioners may use best fitting model curves to assess the character of past growth in terms of the relative growth rate v´/v. However, for the present data also this analysis of the past did depend on how much information about the growth was available at the time when the assessment was done. For, the assessment switched from an initially decreasing relative growth rate, if only seven or eight data points were considered, to an initially increasing relative growth rate, when more data were utilized (Fig. 10).
Availability of data and materials
The method explains the sources of the data. Further, the authors provided supplementary material, namly an spreadsheet (MS Excel) with the optimization results for the full data set and the Mathematica file that produced this Excel file.
Abbreviations
 SSE:

is the sum of squared errors (i.e. the fit residuals)
References
 1.
Schwartz M. A biomathematical approach to clinical tumor growth. Cancer. 1961;14:1272–94.
 2.
Bloom HJ, Richardson WW, Harries EJ. Natural history of untreated breast cancer. Comparison of untreated and treated cases according to histological grade of malignancy. Br Med J. 1962;2:213–21.
 3.
Laird AK. Dynamics of tumor growth. Br J Cancer. 1965;19:278–91.
 4.
Wheldon, T.E. Mathematical models in Cancer research, Bristol (UK): Adam Hilger1988.
 5.
Michor F. Evolutionary dynamics of cancer. Doctoral thesis. Cambridge: Harvard Univ; 2005.
 6.
Gerlee P. The model muddle: in search of tumor growth Laws. Cancer Res. 2013;73:2407–11.
 7.
Benzekry, S., Lamont, C., Beheshti, A., Tracz, A., Ebos, J.M.L., Hlatky, L., Hahnfeldt, P. (2014) Classical Mathematical Models for Description and Prediction of Experimental Tumor Growth. PLoS Computational Biology 2014, 10: e1003800. Published online: DOI https://doi.org/10.1371/journal.pcbi.1003800.
 8.
Norton L, Simon R. Tumor size, sensitivity to therapy, and the design of cancer treatment. Cancer Treatment Reports. 1977;61:1307–17.
 9.
Hillen T, Enderling H, Hahnfeldt P. The tumor growth paradox and immune systemmediated selection for cancer stem cells. Bull Math Biol. 2013;2013(75):161–84.
 10.
Poleszczuk, J., Howard, R., Moros, E.G., Latifi, K., Caudell, J.J., Enderling, H. Predicting patientspecific radiotherapy protocols based on mathematical model choice for Proliferation Saturation Index, Bulletin of Mathematical Biology 2017, 80: 1195–1206. Published online: DOI https://doi.org/10.1007/s1153801702790.
 11.
Bertalanffy, L.v. Quantitative laws in metabolism and growth. Q Rev Biol 1957; 32: 217–231.
 12.
Pütter A. Studien über physiologische Ähnlichkeit. VI. Wachstumsähnlichkeiten. Pflügers Archiv für die Gesamte Physiologie des Menschen und der Tiere. 1920;180:298–340.
 13.
Ohnishi S, Yamakawa T, Akamine T. On the analytical solution for the PütterBertalanffy growth equation. J Theor Biol. 2014;343:174–7.
 14.
Diebner, H.H., Zerjatke, T., Griehl, M., Roeder, I. Metabolism is the tie: The Bertalanffytype cancer growth model as common denominator of various modelling approaches. Biosystems 2018, 167: 1–23. Published online: DOI https://doi.org/10.1016/j.biosystems.2018.03.004.
 15.
Verhulst PF. Notice sur la loi que la population suit dans son accroissement. Correspondence Mathematique et Physique (Ghent). 1838;10:113–21.
 16.
Gompertz B. On the nature of the function expressive of the law of human mortality, and on a new mode of determining the value of life contingencies. Philos Trans R Soc London. 1832;123:513–85.
 17.
Marusic M, Bajzer Z. Generalized twoparameter equations of growth. J Math Anal Appl. 1993;179:446–62.
 18.
Richards FJ. A flexible growth function for empirical use. J Exp Bot. 1959;10:290–300.
 19.
Acemogulu D. Introduction to modern economic growth. University Press: Princeton; 2008.
 20.
Abreu M. Neoclassical regional growth models. In: Fischer M, Nijkamp P, editors. Handbook of regional sciences. Berlin: Springer Verlag; 2019.
 21.
Solow RM. A contribution to the theory of economic growth. Q J Econ. 1956;70:65–94.
 22.
Swan TW. Economic growth and capital accumulation. Economic Record. 1956;32:334–61.
 23.
West GB, Brown JH, Enquist BJ. A general model for ontogenetic growth. Nature. 2001;413:628–31.
 24.
Herman, A.B., Savage, V.M., West, G.B. A quantitative theory of solid tumor growth, metabolic rate and vascularization. PLoS One 2011, 6: e22973. Published online: DOI https://doi.org/10.1371/journal.pone.0022973.
 25.
Bassukas, I.D. Modeling the Tumor Growth Profiles in Xenograft Experiments (Letter). Clinical Cancer Research 2011, 17: 4612. Published online: DOI: https://doi.org/10.1158/10780432.CCR110713.
 26.
Pauly D. The relationship between gill surface area and growth performance in fish: a generalization of von Bertalanffy’s theory of growth. Reports on Marine Research (Berichte der deutschen wissenschaftlichen Kommission für Meeresforschung). 1981;28:25–282.
 27.
Pauly D, Cheung WWL. Sound physiological knowledge and principles in modeling shrinking of fishes under climate change. Global change biology 2017. Published online. https://doi.org/10.1111/gcb.13831.
 28.
Calder WA III. Size, function, and life history. Cambridge: Harvard Univ. Press; 1985.
 29.
Jacobs, J., Rockne, R.C., HawkinsDaarud, A.J., Jackson, P.R., Johnston, S.K., Kinahan, P., Swanson, K.R. Improved model prediction of glioma growth utilizing tissuespecific boundary effects. Mathematical Biosciences 2019, 312: 59–66. Published online: DOI https://doi.org/10.1016/j.mbs.2019.04.004.
 30.
Lowengrub, J.S., Frieboes, H.B., Jin, F., Chuang, Y.L., Li, X., Macklin. P., Wise, S.M., Cristini, V. Nonlinear modelling of cancer: bridging the gap between cells and tumours. Nonlinearity 2010, 23: R1R9.
 31.
Murphy, H., Jaafari, H., Dobrovolny, H.M. Differences in predictions of ODE models of tumor growth: a cautionary example. BMC Cancer 2016, 16: 163–172. Published online: DOI https://doi.org/10.1186/s128850162164x.
 32.
RennerMartin, K., Brunner, N., Kühleitner, M., Nowak, W.G., Scheicher, K. On the exponent in the Von Bertalanffy growth model. PeerJ 2018, 6: e4205. Published online: DOI https://doi.org/10.7717/peerj.4205.
 33.
RennerMartin, K., Brunner, N., Kühleitner, M., Nowak, W.G., Scheicher, K. Optimal and nearoptimal exponentpairs for the BertalanffyPütter growth model. PeerJ 2018, 6: e5973. Published online: DOI https://doi.org/10.7717/peerj.5973.
 34.
Kühleitner M, Brunner N, Nowak WG, RennerMartin K, Scheicher K. Bestfitting growth curves of the von BertalanffyPütter type. Poultry science 2019. Published online. https://doi.org/10.3382/ps/pez122.
 35.
Worschech, A., Chen, N., Yu, Y.A., Zhang, Q., Pos, Z., Weibel, S., Raab, V., Sabatino, M., Monaco, A., Liu, H., Monsurró, V., Buller, R.M., Stroncek, D.F.,Wang, E., Szalay, A.A., Marincola, F.M. Systemic treatment of xenografts with vaccinia virus GLV1h68 reveals the immunologic facet of oncolytic therapy. BMC Genomics 2009; 10: 301. Published online DOI https://doi.org/10.1186/1471216410301.
 36.
Maeland, E. On the comparison of interpolation methods. IEEE Transactions on Medical Imaging 1988, 7: 213–217. Published online: DOI https://doi.org/10.1109/42.7784.
 37.
Adamuthe AC, Thampi GT. Technology forecasting: a case study of computational technologies. Technological forecasting and social change 2019. Published online. https://doi.org/10.1016/j.techfore.2019.03.002.
 38.
Nguimkeu, P. A simple selection test between the Gompertz and Logistic growth models. Technological Forecasting and Social Change 2014, 88: 98–105. Published online: DOI https://doi.org/10.1016/j.techfore.2014.06.017.
 39.
Evans, D.L., Drew, J.H., Leemis, L.M. The Distribution of the KolmogorovSmirnov, Cramervon Mises, and AndersonDarling Test Statistics for Exponential Populations with Estimated Parameters. In Glen, A.G., Leemis, L.M. (Eds.) Computational Probability Applications. New York: Springer Publishing 2017, 165–190.
 40.
Akaike H. A new look at the statistical model identification. IEEE Trans Automatic Control. 1974;19:716–23.
 41.
Burnham KP, Anderson DR. Model selection and multimodel inference: a practical informationtheoretic approach. Berlin: Springer Verlag; 2002.
 42.
Motulsky H, Christopoulos A. Fitting models to biological data using linear and nonlinear regression: a practical guide to curve fitting. Oxford: Univ. Press; 2003.
 43.
Vidal RVV. Applied simulated annealing. Lecture notes in economics and mathematical systems. Berlin: Springer Verlag; 1993.
Acknowledgements
The authors appreciate the insightful comments by the reviewers. In responding to them the authors had the opportunity to improve the paper substantially.
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Correspondence to Manfred Kühleitner.
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Keywords
 Cancer
 Simulated annealing
 Tumor growth
 BertalanffyPütter growth models