Abstract: The purpose of this paper is to investigate the dynamics and statistics of style rotation based on the Barberis–Shleifer model of style switching. Investors in stocks regard the forecasting of style-relative performance, especially style rotation, as highly desirable but difficult to achieve in practice. Whilst we do not claim to be able to do this in an empirical sense, we do provide a theoretical framework for addressing these issues. We develop some new results from the Barberis–Shleifer model which allows us to understand some of the time series properties of styles’ relative performance and determine the statistical properties of the time until a switch between styles. In conclusion, we discuss potential applications of our findings to empirical data.
Acknowledgements
We are grateful to Prof. Ron Smith of Birkbeck, University of London, for the technical suggestion to set ϑ equal to 0.99.
Appendix
Proof of Proposition 1.


which, when resolved, produces the following formulas for coefficients and
:

(b) if, the auxiliary eq. [28] has only one real root and the general solution of eq. [27] is given by

or remembering that and fitting the boundary conditions on
and
, we have a system


which, when resolved, produces the following formulas for coefficients and
:

(c) if , the auxiliary eq. [28] has two complex conjugate roots and the general solution is given by

where and
are complex conjugates too (see e.g., chapter 1.2 of J.D. Hamilton “Time Series Analysis”, 1994), and


Substituting ,
, we have the general solution to have the form

which after remembering the boundary conditions on and
, produces solution of the form given in eq. [32]. Coefficients
and
are given by

where .
Proof of Lemma 1:
Starting with eq. [37] and using the lag operator L, we have

which can be rewritten as

that is , which proves the lemma.
Proof of Proposition 2:
The proof is similar to the proof of Proposition 1, in that we have the same general eq. [41] for the forecast of excess return as we had in eq. [27] for the autocovariance, which means that the solutions to the three cases (a), (b) and (c) which correspond to three different levels of discriminant (positive, nill or negative) will have the same general form. The difference in solutions comes from different boundary (i.e., initial) conditions and is demonstrated below.


where is set by Lemma 1. Therefore we have a system of equations for
?and?
:


which, when solved, produces the following formulas for coefficients and
:


(b) If , the auxiliary eq. [28] has only one real root and the general solution of eq. [41] is given by

or remembering that and fitting the boundary conditions on
and
, we have a system


which, when resolved, produces the following formula for coefficients and?
:


and ,
(c) If , the auxiliary eq. [28] has two complex conjugate roots and the general solution is given by

where and
are complex conjugates too (see e.g., chapter 1.2 of J.D.Hamilton “Time Series Analysis”, 1994), and


Substituting ,
, we have the general solution to have the form

which after remembering the boundary conditions, produces the following formulas for coefficients and
in formula [50]:


where
Proof of Lemma 2:
We are looking for a moving average representation of the kind

for the process defined by eq. [37]. Putting formula [54] into eq. [37] we obtain

After equating coefficients of , we find that the coefficients have to satisfy the following conditions:



Assuming a solution of the kind

we immediately derive that the solution has the form

with eqs. (A.30) and (A.31) serving as the boundary conditions, which we use to find the constants and
. Resolving this system of two equations with two unknowns we derive that

as required.
Proof of Lemma 3:
This lemma simply summarises the conditions under which the formula [60] for the lag at which the first switch occurs is well-defined and therefore, such lag can be computed. The proof therefore is straight-forward.
Proof of Proposition 3:
The proof of this proposition immediately follows from the infinite moving average representation [47], the definition of the h-step ahead forecast:

and the i.i.d. assumption in relation to all .
Proof of Lemma 4:
The proof of this lemma simply follows from starting with eqs. [2] and [5], inserting the definitions of and
of [3], and collecting all components with
and
together.
Proof of Proposition 4:
We start from eqs. [11] and [14], where we use formula [13] which is the definition of ϕ:


We then aggregate across all equities in each style using formulas [4] and insert formulas [62] and [63] for the aggregate demand for equities in each two styles obtained in Lemma 4, which then leads us to formula [64].
References
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- 1
We indeed experienced a unit root problem in our application of the model to a pair of two equity indices representing emerging and developed equities, refer to Golosov and Satchell (2012) (see Section 7 for the reference).
©2014 by Walter de Gruyter Berlin / Boston
Articles in the same Issue
- Frontmatter
- Modeling Style Rotation: Switching and Re-switching
- Asymptotically Unbiased Estimation of Autocovariances and Autocorrelations with Panel Data in the Presence of Individual and Time Effects
- Valid Locally Uniform Edgeworth Expansions for a Class of Weakly Dependent Processes or Sequences of Smooth Transformations
- Optimal Signal Extraction with Correlated Components
Articles in the same Issue
- Frontmatter
- Modeling Style Rotation: Switching and Re-switching
- Asymptotically Unbiased Estimation of Autocovariances and Autocorrelations with Panel Data in the Presence of Individual and Time Effects
- Valid Locally Uniform Edgeworth Expansions for a Class of Weakly Dependent Processes or Sequences of Smooth Transformations
- Optimal Signal Extraction with Correlated Components